pywafo/wafo/stats/stats.py

# Copyright (c) Gary Strangman.  All rights reserved
#
# Disclaimer
#
# This software is provided "as-is".  There are no expressed or implied
# warranties of any kind, including, but not limited to, the warranties
# of merchantability and fitness for a given application.  In no event
# shall Gary Strangman be liable for any direct, indirect, incidental,
# special, exemplary or consequential damages (including, but not limited
# to, loss of use, data or profits, or business interruption) however
# caused and on any theory of liability, whether in contract, strict
# liability or tort (including negligence or otherwise) arising in any way
# out of the use of this software, even if advised of the possibility of
# such damage.
#

#
# Heavily adapted for use by SciPy 2002 by Travis Oliphant
"""
A collection of basic statistical functions for python.  The function
names appear below.

 Some scalar functions defined here are also available in the scipy.special
 package where they work on arbitrary sized arrays.

Disclaimers:  The function list is obviously incomplete and, worse, the
functions are not optimized.  All functions have been tested (some more
so than others), but they are far from bulletproof.  Thus, as with any
free software, no warranty or guarantee is expressed or implied. :-)  A
few extra functions that don't appear in the list below can be found by
interested treasure-hunters.  These functions don't necessarily have
both list and array versions but were deemed useful.

Central Tendency
----------------
.. autosummary::
   :toctree: generated/

    gmean
    hmean
    mode

Moments
-------
.. autosummary::
   :toctree: generated/

    moment
    variation
    skew
    kurtosis
    normaltest

Moments Handling NaN:

.. autosummary::
   :toctree: generated/

    nanmean
    nanmedian
    nanstd

Altered Versions
----------------
.. autosummary::
   :toctree: generated/

    tmean
    tvar
    tstd
    tsem
    describe

Frequency Stats
---------------
.. autosummary::
   :toctree: generated/

    itemfreq
    scoreatpercentile
    percentileofscore
    histogram
    cumfreq
    relfreq

Variability
-----------
.. autosummary::
   :toctree: generated/

    obrientransform
    signaltonoise
    sem

Trimming Functions
------------------
.. autosummary::
   :toctree: generated/

   threshold
   trimboth
   trim1

Correlation Functions
---------------------
.. autosummary::
   :toctree: generated/

   pearsonr
   fisher_exact
   spearmanr
   pointbiserialr
   kendalltau
   linregress
   theilslopes

Inferential Stats
-----------------
.. autosummary::
   :toctree: generated/

   ttest_1samp
   ttest_ind
   ttest_rel
   chisquare
   power_divergence
   ks_2samp
   mannwhitneyu
   ranksums
   wilcoxon
   kruskal
   friedmanchisquare

Probability Calculations
------------------------
.. autosummary::
   :toctree: generated/

   chisqprob
   zprob
   fprob
   betai

ANOVA Functions
---------------
.. autosummary::
   :toctree: generated/

   f_oneway
   f_value

Support Functions
-----------------
.. autosummary::
   :toctree: generated/

   ss
   square_of_sums
   rankdata

References
----------
.. [CRCProbStat2000] Zwillinger, D. and Kokoska, S. (2000). CRC Standard
   Probability and Statistics Tables and Formulae. Chapman & Hall: New
   York. 2000.

"""

from __future__ import division, print_function, absolute_import

import warnings
import math

from scipy.lib.six import xrange

# friedmanchisquare patch uses python sum
pysum = sum  # save it before it gets overwritten

# Scipy imports.
from scipy.lib.six import callable, string_types
from numpy import array, asarray, ma, zeros, sum
import scipy.special as special
import scipy.linalg as linalg
import numpy as np

from . import futil
from . import distributions
try:
    from scipy.stats._rank import rankdata, tiecorrect
except:
    rankdata = tiecorrect = None
__all__ = ['find_repeats', 'gmean', 'hmean', 'mode', 'tmean', 'tvar',
           'tmin', 'tmax', 'tstd', 'tsem', 'moment', 'variation',
           'skew', 'kurtosis', 'describe', 'skewtest', 'kurtosistest',
           'normaltest', 'jarque_bera', 'itemfreq',
           'scoreatpercentile', 'percentileofscore', 'histogram',
           'histogram2', 'cumfreq', 'relfreq', 'obrientransform',
           'signaltonoise', 'sem', 'zmap', 'zscore', 'threshold',
           'sigmaclip', 'trimboth', 'trim1', 'trim_mean', 'f_oneway',
           'pearsonr', 'fisher_exact', 'spearmanr', 'pointbiserialr',
           'kendalltau', 'linregress', 'theilslopes', 'ttest_1samp',
           'ttest_ind', 'ttest_rel', 'kstest', 'chisquare',
           'power_divergence', 'ks_2samp', 'mannwhitneyu',
           'tiecorrect', 'ranksums', 'kruskal', 'friedmanchisquare',
           'zprob', 'chisqprob', 'ksprob', 'fprob', 'betai',
           'f_value_wilks_lambda', 'f_value', 'f_value_multivariate',
           'ss', 'square_of_sums', 'fastsort', 'rankdata', 'nanmean',
           'nanstd', 'nanmedian', ]


def _chk_asarray(a, axis):
    if axis is None:
        a = np.ravel(a)
        outaxis = 0
    else:
        a = np.asarray(a)
        outaxis = axis
    return a, outaxis


def _chk2_asarray(a, b, axis):
    if axis is None:
        a = np.ravel(a)
        b = np.ravel(b)
        outaxis = 0
    else:
        a = np.asarray(a)
        b = np.asarray(b)
        outaxis = axis
    return a, b, outaxis


def find_repeats(arr):
    """
    Find repeats and repeat counts.

    Parameters
    ----------
    arr : array_like
        Input array

    Returns
    -------
    find_repeats : tuple
        Returns a tuple of two 1-D ndarrays.  The first ndarray are the repeats
        as sorted, unique values that are repeated in `arr`.  The second
        ndarray are the counts mapped one-to-one of the repeated values
        in the first ndarray.

    Examples
    --------
    >>> import scipy.stats as stats
    >>> stats.find_repeats([2, 1, 2, 3, 2, 2, 5])
    (array([ 2. ]), array([ 4 ], dtype=int32)

    >>> stats.find_repeats([[10, 20, 1, 2], [5, 5, 4, 4]])
    (array([ 4., 5.]), array([2, 2], dtype=int32))

    """
    v1,v2, n = futil.dfreps(arr)
    return v1[:n],v2[:n]

#######
### NAN friendly functions
########


def nanmean(x, axis=0):
    """
    Compute the mean over the given axis ignoring nans.

    Parameters
    ----------
    x : ndarray
        Input array.
    axis : int, optional
        Axis along which the mean is computed. Default is 0, i.e. the
        first axis.

    Returns
    -------
    m : float
        The mean of `x`, ignoring nans.

    See Also
    --------
    nanstd, nanmedian

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.linspace(0, 4, 3)
    >>> a
    array([ 0.,  2.,  4.])
    >>> a[-1] = np.nan
    >>> stats.nanmean(a)
    1.0

    """
    x, axis = _chk_asarray(x, axis)
    x = x.copy()
    Norig = x.shape[axis]
    mask = np.isnan(x)
    factor = 1.0 - np.sum(mask, axis) / Norig

    x[mask] = 0.0
    return np.mean(x, axis) / factor


def nanstd(x, axis=0, bias=False):
    """
    Compute the standard deviation over the given axis, ignoring nans.

    Parameters
    ----------
    x : array_like
        Input array.
    axis : int or None, optional
        Axis along which the standard deviation is computed. Default is 0.
        If None, compute over the whole array `x`.
    bias : bool, optional
        If True, the biased (normalized by N) definition is used. If False
        (default), the unbiased definition is used.

    Returns
    -------
    s : float
        The standard deviation.

    See Also
    --------
    nanmean, nanmedian

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.arange(10, dtype=float)
    >>> a[1:3] = np.nan
    >>> np.std(a)
    nan
    >>> stats.nanstd(a)
    2.9154759474226504
    >>> stats.nanstd(a.reshape(2, 5), axis=1)
    array([ 2.0817,  1.5811])
    >>> stats.nanstd(a.reshape(2, 5), axis=None)
    2.9154759474226504

    """
    x, axis = _chk_asarray(x, axis)
    x = x.copy()
    Norig = x.shape[axis]

    mask = np.isnan(x)
    Nnan = np.sum(mask, axis) * 1.0
    n = Norig - Nnan

    x[mask] = 0.0
    m1 = np.sum(x, axis) / n

    if axis:
        d = x - np.expand_dims(m1, axis)
    else:
        d = x - m1

    d *= d

    m2 = np.sum(d, axis) - m1 * m1 * Nnan

    if bias:
        m2c = m2 / n
    else:
        m2c = m2 / (n - 1.0)

    return np.sqrt(m2c)


def _nanmedian(arr1d):  # This only works on 1d arrays
    """Private function for rank a arrays. Compute the median ignoring Nan.

    Parameters
    ----------
    arr1d : ndarray
        Input array, of rank 1.

    Results
    -------
    m : float
        The median.
    """
    x = arr1d.copy()
    c = np.isnan(x)
    s = np.where(c)[0]
    if s.size == x.size:
        warnings.warn("All-NaN slice encountered", RuntimeWarning)
        return np.nan
    elif s.size != 0:
        # select non-nans at end of array
        enonan = x[-s.size:][~c[-s.size:]]
        # fill nans in beginning of array with non-nans of end
        x[s[:enonan.size]] = enonan
        # slice nans away
        x = x[:-s.size]
    return np.median(x, overwrite_input=True)


def nanmedian(x, axis=0):
    """
    Compute the median along the given axis ignoring nan values.

    Parameters
    ----------
    x : array_like
        Input array.
    axis : int, optional
        Axis along which the median is computed. Default is 0, i.e. the
        first axis.

    Returns
    -------
    m : float
        The median of `x` along `axis`.

    See Also
    --------
    nanstd, nanmean, numpy.nanmedian

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.array([0, 3, 1, 5, 5, np.nan])
    >>> stats.nanmedian(a)
    array(3.0)

    >>> b = np.array([0, 3, 1, 5, 5, np.nan, 5])
    >>> stats.nanmedian(b)
    array(4.0)

    Example with axis:

    >>> c = np.arange(30.).reshape(5,6)
    >>> idx = np.array([False, False, False, True, False] * 6).reshape(5,6)
    >>> c[idx] = np.nan
    >>> c
    array([[  0.,   1.,   2.,  nan,   4.,   5.],
           [  6.,   7.,  nan,   9.,  10.,  11.],
           [ 12.,  nan,  14.,  15.,  16.,  17.],
           [ nan,  19.,  20.,  21.,  22.,  nan],
           [ 24.,  25.,  26.,  27.,  nan,  29.]])
    >>> stats.nanmedian(c, axis=1)
    array([  2. ,   9. ,  15. ,  20.5,  26. ])

    """
    x, axis = _chk_asarray(x, axis)
    if x.ndim == 0:
        return float(x.item())
    if hasattr(np, 'nanmedian'):  # numpy 1.9 faster for some cases
        return np.nanmedian(x, axis)
    x = np.apply_along_axis(_nanmedian, axis, x)
    if x.ndim == 0:
        x = float(x.item())
    return x


#####################################
########  CENTRAL TENDENCY  ########
#####################################


def gmean(a, axis=0, dtype=None):
    """
    Compute the geometric mean along the specified axis.

    Returns the geometric average of the array elements.
    That is:  n-th root of (x1 * x2 * ... * xn)

    Parameters
    ----------
    a : array_like
        Input array or object that can be converted to an array.
    axis : int, optional, default axis=0
        Axis along which the geometric mean is computed.
    dtype : dtype, optional
        Type of the returned array and of the accumulator in which the
        elements are summed. If dtype is not specified, it defaults to the
        dtype of a, unless a has an integer dtype with a precision less than
        that of the default platform integer. In that case, the default
        platform integer is used.

    Returns
    -------
    gmean : ndarray
        see dtype parameter above

    See Also
    --------
    numpy.mean : Arithmetic average
    numpy.average : Weighted average
    hmean : Harmonic mean

    Notes
    -----
    The geometric average is computed over a single dimension of the input
    array, axis=0 by default, or all values in the array if axis=None.
    float64 intermediate and return values are used for integer inputs.

    Use masked arrays to ignore any non-finite values in the input or that
    arise in the calculations such as Not a Number and infinity because masked
    arrays automatically mask any non-finite values.

    """
    if not isinstance(a, np.ndarray):  # if not an ndarray object attempt to convert it
        log_a = np.log(np.array(a, dtype=dtype))
    elif dtype:  # Must change the default dtype allowing array type
        if isinstance(a,np.ma.MaskedArray):
            log_a = np.log(np.ma.asarray(a, dtype=dtype))
        else:
            log_a = np.log(np.asarray(a, dtype=dtype))
    else:
        log_a = np.log(a)
    return np.exp(log_a.mean(axis=axis))


def hmean(a, axis=0, dtype=None):
    """
    Calculates the harmonic mean along the specified axis.

    That is:  n / (1/x1 + 1/x2 + ... + 1/xn)

    Parameters
    ----------
    a : array_like
        Input array, masked array or object that can be converted to an array.
    axis : int, optional, default axis=0
        Axis along which the harmonic mean is computed.
    dtype : dtype, optional
        Type of the returned array and of the accumulator in which the
        elements are summed. If `dtype` is not specified, it defaults to the
        dtype of `a`, unless `a` has an integer `dtype` with a precision less
        than that of the default platform integer. In that case, the default
        platform integer is used.

    Returns
    -------
    hmean : ndarray
        see `dtype` parameter above

    See Also
    --------
    numpy.mean : Arithmetic average
    numpy.average : Weighted average
    gmean : Geometric mean

    Notes
    -----
    The harmonic mean is computed over a single dimension of the input
    array, axis=0 by default, or all values in the array if axis=None.
    float64 intermediate and return values are used for integer inputs.

    Use masked arrays to ignore any non-finite values in the input or that
    arise in the calculations such as Not a Number and infinity.

    """
    if not isinstance(a, np.ndarray):
        a = np.array(a, dtype=dtype)
    if np.all(a > 0):  # Harmonic mean only defined if greater than zero
        if isinstance(a, np.ma.MaskedArray):
            size = a.count(axis)
        else:
            if axis is None:
                a = a.ravel()
                size = a.shape[0]
            else:
                size = a.shape[axis]
        return size / np.sum(1.0/a, axis=axis, dtype=dtype)
    else:
        raise ValueError("Harmonic mean only defined if all elements greater than zero")


def mode(a, axis=0):
    """
    Returns an array of the modal (most common) value in the passed array.

    If there is more than one such value, only the first is returned.
    The bin-count for the modal bins is also returned.

    Parameters
    ----------
    a : array_like
        n-dimensional array of which to find mode(s).
    axis : int, optional
        Axis along which to operate. Default is 0, i.e. the first axis.

    Returns
    -------
    vals : ndarray
        Array of modal values.
    counts : ndarray
        Array of counts for each mode.

    Examples
    --------
    >>> a = np.array([[6, 8, 3, 0],
                      [3, 2, 1, 7],
                      [8, 1, 8, 4],
                      [5, 3, 0, 5],
                      [4, 7, 5, 9]])
    >>> from scipy import stats
    >>> stats.mode(a)
    (array([[ 3.,  1.,  0.,  0.]]), array([[ 1.,  1.,  1.,  1.]]))

    To get mode of whole array, specify axis=None:

    >>> stats.mode(a, axis=None)
    (array([ 3.]), array([ 3.]))

    """
    a, axis = _chk_asarray(a, axis)
    scores = np.unique(np.ravel(a))       # get ALL unique values
    testshape = list(a.shape)
    testshape[axis] = 1
    oldmostfreq = np.zeros(testshape, dtype=a.dtype)
    oldcounts = np.zeros(testshape)
    for score in scores:
        template = (a == score)
        counts = np.expand_dims(np.sum(template, axis),axis)
        mostfrequent = np.where(counts > oldcounts, score, oldmostfreq)
        oldcounts = np.maximum(counts, oldcounts)
        oldmostfreq = mostfrequent
    return mostfrequent, oldcounts


def mask_to_limits(a, limits, inclusive):
    """Mask an array for values outside of given limits.

    This is primarily a utility function.

    Parameters
    ----------
    a : array
    limits : (float or None, float or None)
        A tuple consisting of the (lower limit, upper limit).  Values in the
        input array less than the lower limit or greater than the upper limit
        will be masked out. None implies no limit.
    inclusive : (bool, bool)
        A tuple consisting of the (lower flag, upper flag).  These flags
        determine whether values exactly equal to lower or upper are allowed.

    Returns
    -------
    A MaskedArray.

    Raises
    ------
    A ValueError if there are no values within the given limits.
    """
    lower_limit, upper_limit = limits
    lower_include, upper_include = inclusive
    am = ma.MaskedArray(a)
    if lower_limit is not None:
        if lower_include:
            am = ma.masked_less(am, lower_limit)
        else:
            am = ma.masked_less_equal(am, lower_limit)

    if upper_limit is not None:
        if upper_include:
            am = ma.masked_greater(am, upper_limit)
        else:
            am = ma.masked_greater_equal(am, upper_limit)

    if am.count() == 0:
        raise ValueError("No array values within given limits")

    return am


def tmean(a, limits=None, inclusive=(True, True)):
    """
    Compute the trimmed mean.

    This function finds the arithmetic mean of given values, ignoring values
    outside the given `limits`.

    Parameters
    ----------
    a : array_like
        Array of values.
    limits : None or (lower limit, upper limit), optional
        Values in the input array less than the lower limit or greater than the
        upper limit will be ignored.  When limits is None (default), then all
        values are used.  Either of the limit values in the tuple can also be
        None representing a half-open interval.
    inclusive : (bool, bool), optional
        A tuple consisting of the (lower flag, upper flag).  These flags
        determine whether values exactly equal to the lower or upper limits
        are included.  The default value is (True, True).

    Returns
    -------
    tmean : float

    """
    a = asarray(a)
    if limits is None:
        return np.mean(a, None)

    am = mask_to_limits(a.ravel(), limits, inclusive)
    return am.mean()


def masked_var(am):
    m = am.mean()
    s = ma.add.reduce((am - m)**2)
    n = am.count() - 1.0
    return s / n


def tvar(a, limits=None, inclusive=(True, True)):
    """
    Compute the trimmed variance

    This function computes the sample variance of an array of values,
    while ignoring values which are outside of given `limits`.

    Parameters
    ----------
    a : array_like
        Array of values.
    limits : None or (lower limit, upper limit), optional
        Values in the input array less than the lower limit or greater than the
        upper limit will be ignored. When limits is None, then all values are
        used. Either of the limit values in the tuple can also be None
        representing a half-open interval.  The default value is None.
    inclusive : (bool, bool), optional
        A tuple consisting of the (lower flag, upper flag).  These flags
        determine whether values exactly equal to the lower or upper limits
        are included.  The default value is (True, True).

    Returns
    -------
    tvar : float
        Trimmed variance.

    Notes
    -----
    `tvar` computes the unbiased sample variance, i.e. it uses a correction
    factor ``n / (n - 1)``.

    """
    a = asarray(a)
    a = a.astype(float).ravel()
    if limits is None:
        n = len(a)
        return a.var()*(n/(n-1.))
    am = mask_to_limits(a, limits, inclusive)
    return masked_var(am)


def tmin(a, lowerlimit=None, axis=0, inclusive=True):
    """
    Compute the trimmed minimum

    This function finds the miminum value of an array `a` along the
    specified axis, but only considering values greater than a specified
    lower limit.

    Parameters
    ----------
    a : array_like
        array of values
    lowerlimit : None or float, optional
        Values in the input array less than the given limit will be ignored.
        When lowerlimit is None, then all values are used. The default value
        is None.
    axis : None or int, optional
        Operate along this axis.  None means to use the flattened array and
        the default is zero
    inclusive : {True, False}, optional
        This flag determines whether values exactly equal to the lower limit
        are included.  The default value is True.

    Returns
    -------
    tmin : float

    """
    a, axis = _chk_asarray(a, axis)
    am = mask_to_limits(a, (lowerlimit, None), (inclusive, False))
    return ma.minimum.reduce(am, axis)


def tmax(a, upperlimit=None, axis=0, inclusive=True):
    """
    Compute the trimmed maximum

    This function computes the maximum value of an array along a given axis,
    while ignoring values larger than a specified upper limit.

    Parameters
    ----------
    a : array_like
        array of values
    upperlimit : None or float, optional
        Values in the input array greater than the given limit will be ignored.
        When upperlimit is None, then all values are used. The default value
        is None.
    axis : None or int, optional
        Operate along this axis.  None means to use the flattened array and
        the default is zero.
    inclusive : {True, False}, optional
        This flag determines whether values exactly equal to the upper limit
        are included.  The default value is True.

    Returns
    -------
    tmax : float

    """
    a, axis = _chk_asarray(a, axis)
    am = mask_to_limits(a, (None, upperlimit), (False, inclusive))
    return ma.maximum.reduce(am, axis)


def tstd(a, limits=None, inclusive=(True, True)):
    """
    Compute the trimmed sample standard deviation

    This function finds the sample standard deviation of given values,
    ignoring values outside the given `limits`.

    Parameters
    ----------
    a : array_like
        array of values
    limits : None or (lower limit, upper limit), optional
        Values in the input array less than the lower limit or greater than the
        upper limit will be ignored. When limits is None, then all values are
        used. Either of the limit values in the tuple can also be None
        representing a half-open interval.  The default value is None.
    inclusive : (bool, bool), optional
        A tuple consisting of the (lower flag, upper flag).  These flags
        determine whether values exactly equal to the lower or upper limits
        are included.  The default value is (True, True).

    Returns
    -------
    tstd : float

    Notes
    -----
    `tstd` computes the unbiased sample standard deviation, i.e. it uses a
    correction factor ``n / (n - 1)``.

    """
    return np.sqrt(tvar(a, limits, inclusive))


def tsem(a, limits=None, inclusive=(True, True)):
    """
    Compute the trimmed standard error of the mean.

    This function finds the standard error of the mean for given
    values, ignoring values outside the given `limits`.

    Parameters
    ----------
    a : array_like
        array of values
    limits : None or (lower limit, upper limit), optional
        Values in the input array less than the lower limit or greater than the
        upper limit will be ignored. When limits is None, then all values are
        used. Either of the limit values in the tuple can also be None
        representing a half-open interval.  The default value is None.
    inclusive : (bool, bool), optional
        A tuple consisting of the (lower flag, upper flag).  These flags
        determine whether values exactly equal to the lower or upper limits
        are included.  The default value is (True, True).

    Returns
    -------
    tsem : float

    Notes
    -----
    `tsem` uses unbiased sample standard deviation, i.e. it uses a
    correction factor ``n / (n - 1)``.

    """
    a = np.asarray(a).ravel()
    if limits is None:
        return a.std(ddof=1) / np.sqrt(a.size)

    am = mask_to_limits(a, limits, inclusive)
    sd = np.sqrt(masked_var(am))
    return sd / np.sqrt(am.count())


#####################################
############  MOMENTS  #############
#####################################

def moment(a, moment=1, axis=0):
    """
    Calculates the nth moment about the mean for a sample.

    Generally used to calculate coefficients of skewness and
    kurtosis.

    Parameters
    ----------
    a : array_like
       data
    moment : int
       order of central moment that is returned
    axis : int or None
       Axis along which the central moment is computed. If None, then the data
       array is raveled. The default axis is zero.

    Returns
    -------
    n-th central moment : ndarray or float
       The appropriate moment along the given axis or over all values if axis
       is None. The denominator for the moment calculation is the number of
       observations, no degrees of freedom correction is done.

    """
    a, axis = _chk_asarray(a, axis)
    if moment == 1:
        # By definition the first moment about the mean is 0.
        shape = list(a.shape)
        del shape[axis]
        if shape:
            # return an actual array of the appropriate shape
            return np.zeros(shape, dtype=float)
        else:
            # the input was 1D, so return a scalar instead of a rank-0 array
            return np.float64(0.0)
    else:
        mn = np.expand_dims(np.mean(a,axis), axis)
        s = np.power((a-mn), moment)
        return np.mean(s, axis)


def variation(a, axis=0):
    """
    Computes the coefficient of variation, the ratio of the biased standard
    deviation to the mean.

    Parameters
    ----------
    a : array_like
        Input array.
    axis : int or None
        Axis along which to calculate the coefficient of variation.

    References
    ----------
    .. [1] Zwillinger, D. and Kokoska, S. (2000). CRC Standard
       Probability and Statistics Tables and Formulae. Chapman & Hall: New
       York. 2000.

    """
    a, axis = _chk_asarray(a, axis)
    return a.std(axis)/a.mean(axis)


def skew(a, axis=0, bias=True):
    """
    Computes the skewness of a data set.

    For normally distributed data, the skewness should be about 0. A skewness
    value > 0 means that there is more weight in the left tail of the
    distribution. The function `skewtest` can be used to determine if the
    skewness value is close enough to 0, statistically speaking.

    Parameters
    ----------
    a : ndarray
        data
    axis : int or None
        axis along which skewness is calculated
    bias : bool
        If False, then the calculations are corrected for statistical bias.

    Returns
    -------
    skewness : ndarray
        The skewness of values along an axis, returning 0 where all values are
        equal.

    References
    ----------
    [CRCProbStat2000]_ Section 2.2.24.1

    .. [CRCProbStat2000] Zwillinger, D. and Kokoska, S. (2000). CRC Standard
       Probability and Statistics Tables and Formulae. Chapman & Hall: New
       York. 2000.

    """
    a, axis = _chk_asarray(a,axis)
    n = a.shape[axis]
    m2 = moment(a, 2, axis)
    m3 = moment(a, 3, axis)
    zero = (m2 == 0)
    vals = np.where(zero, 0, m3 / m2**1.5)
    if not bias:
        can_correct = (n > 2) & (m2 > 0)
        if can_correct.any():
            m2 = np.extract(can_correct, m2)
            m3 = np.extract(can_correct, m3)
            nval = np.sqrt((n-1.0)*n)/(n-2.0)*m3/m2**1.5
            np.place(vals, can_correct, nval)
    if vals.ndim == 0:
        return vals.item()
    return vals


def kurtosis(a, axis=0, fisher=True, bias=True):
    """
    Computes the kurtosis (Fisher or Pearson) of a dataset.

    Kurtosis is the fourth central moment divided by the square of the
    variance. If Fisher's definition is used, then 3.0 is subtracted from
    the result to give 0.0 for a normal distribution.

    If bias is False then the kurtosis is calculated using k statistics to
    eliminate bias coming from biased moment estimators

    Use `kurtosistest` to see if result is close enough to normal.

    Parameters
    ----------
    a : array
        data for which the kurtosis is calculated
    axis : int or None
        Axis along which the kurtosis is calculated
    fisher : bool
        If True, Fisher's definition is used (normal ==> 0.0). If False,
        Pearson's definition is used (normal ==> 3.0).
    bias : bool
        If False, then the calculations are corrected for statistical bias.

    Returns
    -------
    kurtosis : array
        The kurtosis of values along an axis. If all values are equal,
        return -3 for Fisher's definition and 0 for Pearson's definition.

    References
    ----------
    .. [1] Zwillinger, D. and Kokoska, S. (2000). CRC Standard
       Probability and Statistics Tables and Formulae. Chapman & Hall: New
       York. 2000.

    """
    a, axis = _chk_asarray(a, axis)
    n = a.shape[axis]
    m2 = moment(a,2,axis)
    m4 = moment(a,4,axis)
    zero = (m2 == 0)
    olderr = np.seterr(all='ignore')
    try:
        vals = np.where(zero, 0, m4 / m2**2.0)
    finally:
        np.seterr(**olderr)

    if not bias:
        can_correct = (n > 3) & (m2 > 0)
        if can_correct.any():
            m2 = np.extract(can_correct, m2)
            m4 = np.extract(can_correct, m4)
            nval = 1.0/(n-2)/(n-3)*((n*n-1.0)*m4/m2**2.0-3*(n-1)**2.0)
            np.place(vals, can_correct, nval+3.0)

    if vals.ndim == 0:
        vals = vals.item()  # array scalar

    if fisher:
        return vals - 3
    else:
        return vals


def describe(a, axis=0, ddof=1):
    """
    Computes several descriptive statistics of the passed array.

    Parameters
    ----------
    a : array_like
       Input data.
    axis : int, optional
       Axis along which statistics are calculated.  If axis is None, then data
       array is raveled.  The default axis is zero.
    ddof : int, optional
        Delta degrees of freedom.  Default is 1.

    Returns
    -------
    size of the data : int
       length of data along axis
    (min, max): tuple of ndarrays or floats
       minimum and maximum value of data array
    arithmetic mean : ndarray or float
       mean of data along axis
    unbiased variance : ndarray or float
       variance of the data along axis, denominator is number of observations
       minus one.
    biased skewness : ndarray or float
       skewness, based on moment calculations with denominator equal to the
       number of observations, i.e. no degrees of freedom correction
    biased kurtosis : ndarray or float
       kurtosis (Fisher), the kurtosis is normalized so that it is zero for the
       normal distribution. No degrees of freedom or bias correction is used.

    See Also
    --------
    skew, kurtosis

    """
    a, axis = _chk_asarray(a, axis)
    n = a.shape[axis]
    mm = (np.min(a, axis=axis), np.max(a, axis=axis))
    m = np.mean(a, axis=axis)
    v = np.var(a, axis=axis, ddof=ddof)
    sk = skew(a, axis)
    kurt = kurtosis(a, axis)
    return n, mm, m, v, sk, kurt

#####################################
########  NORMALITY TESTS  ##########
#####################################


def skewtest(a, axis=0):
    """
    Tests whether the skew is different from the normal distribution.

    This function tests the null hypothesis that the skewness of
    the population that the sample was drawn from is the same
    as that of a corresponding normal distribution.

    Parameters
    ----------
    a : array
    axis : int or None

    Returns
    -------
    z-score : float
        The computed z-score for this test.
    p-value : float
        a 2-sided p-value for the hypothesis test

    Notes
    -----
    The sample size must be at least 8.

    """
    a, axis = _chk_asarray(a, axis)
    if axis is None:
        a = np.ravel(a)
        axis = 0
    b2 = skew(a, axis)
    n = float(a.shape[axis])
    if n < 8:
        raise ValueError(
            "skewtest is not valid with less than 8 samples; %i samples"
            " were given." % int(n))
    y = b2 * math.sqrt(((n + 1) * (n + 3)) / (6.0 * (n - 2)))
    beta2 = (3.0 * (n * n + 27 * n - 70) * (n + 1) * (n + 3) /
            ((n - 2.0) * (n + 5) * (n + 7) * (n + 9)))
    W2 = -1 + math.sqrt(2 * (beta2 - 1))
    delta = 1 / math.sqrt(0.5 * math.log(W2))
    alpha = math.sqrt(2.0 / (W2 - 1))
    y = np.where(y == 0, 1, y)
    Z = delta * np.log(y / alpha + np.sqrt((y / alpha) ** 2 + 1))
    return Z, 2 * distributions.norm.sf(np.abs(Z))


def kurtosistest(a, axis=0):
    """
    Tests whether a dataset has normal kurtosis

    This function tests the null hypothesis that the kurtosis
    of the population from which the sample was drawn is that
    of the normal distribution: ``kurtosis = 3(n-1)/(n+1)``.

    Parameters
    ----------
    a : array
        array of the sample data
    axis : int or None
        the axis to operate along, or None to work on the whole array.
        The default is the first axis.

    Returns
    -------
    z-score : float
        The computed z-score for this test.
    p-value : float
        The 2-sided p-value for the hypothesis test

    Notes
    -----
    Valid only for n>20.  The Z-score is set to 0 for bad entries.

    """
    a, axis = _chk_asarray(a, axis)
    n = float(a.shape[axis])
    if n < 5:
        raise ValueError(
            "kurtosistest requires at least 5 observations; %i observations"
            " were given." % int(n))
    if n < 20:
        warnings.warn(
            "kurtosistest only valid for n>=20 ... continuing anyway, n=%i" %
            int(n))
    b2 = kurtosis(a, axis, fisher=False)
    E = 3.0*(n-1) / (n+1)
    varb2 = 24.0*n*(n-2)*(n-3) / ((n+1)*(n+1.)*(n+3)*(n+5))
    x = (b2-E)/np.sqrt(varb2)
    sqrtbeta1 = 6.0*(n*n-5*n+2)/((n+7)*(n+9)) * np.sqrt((6.0*(n+3)*(n+5)) /
                                                       (n*(n-2)*(n-3)))
    A = 6.0 + 8.0/sqrtbeta1 * (2.0/sqrtbeta1 + np.sqrt(1+4.0/(sqrtbeta1**2)))
    term1 = 1 - 2/(9.0*A)
    denom = 1 + x*np.sqrt(2/(A-4.0))
    denom = np.where(denom < 0, 99, denom)
    term2 = np.where(denom < 0, term1, np.power((1-2.0/A)/denom,1/3.0))
    Z = (term1 - term2) / np.sqrt(2/(9.0*A))
    Z = np.where(denom == 99, 0, Z)
    if Z.ndim == 0:
        Z = Z[()]
    # JPNote: p-value sometimes larger than 1
    # zprob uses upper tail, so Z needs to be positive
    return Z, 2 * distributions.norm.sf(np.abs(Z))


def normaltest(a, axis=0):
    """
    Tests whether a sample differs from a normal distribution.

    This function tests the null hypothesis that a sample comes
    from a normal distribution.  It is based on D'Agostino and
    Pearson's [1]_, [2]_ test that combines skew and kurtosis to
    produce an omnibus test of normality.


    Parameters
    ----------
    a : array_like
        The array containing the data to be tested.
    axis : int or None
        If None, the array is treated as a single data set, regardless of
        its shape.  Otherwise, each 1-d array along axis `axis` is tested.

    Returns
    -------
    k2 : float or array
        `s^2 + k^2`, where `s` is the z-score returned by `skewtest` and
        `k` is the z-score returned by `kurtosistest`.
    p-value : float or array
       A 2-sided chi squared probability for the hypothesis test.

    References
    ----------
    .. [1] D'Agostino, R. B. (1971), "An omnibus test of normality for
           moderate and large sample size," Biometrika, 58, 341-348

    .. [2] D'Agostino, R. and Pearson, E. S. (1973), "Testing for
           departures from normality," Biometrika, 60, 613-622

    """
    a, axis = _chk_asarray(a, axis)
    s, _ = skewtest(a, axis)
    k, _ = kurtosistest(a, axis)
    k2 = s*s + k*k
    return k2, chisqprob(k2,2)


def jarque_bera(x):
    """
    Perform the Jarque-Bera goodness of fit test on sample data.

    The Jarque-Bera test tests whether the sample data has the skewness and
    kurtosis matching a normal distribution.

    Note that this test only works for a large enough number of data samples
    (>2000) as the test statistic asymptotically has a Chi-squared distribution
    with 2 degrees of freedom.

    Parameters
    ----------
    x : array_like
        Observations of a random variable.

    Returns
    -------
    jb_value : float
        The test statistic.
    p : float
        The p-value for the hypothesis test.

    References
    ----------
    .. [1] Jarque, C. and Bera, A. (1980) "Efficient tests for normality,
           homoscedasticity and serial independence of regression residuals",
           6 Econometric Letters 255-259.

    Examples
    --------
    >>> from scipy import stats
    >>> np.random.seed(987654321)
    >>> x = np.random.normal(0, 1, 100000)
    >>> y = np.random.rayleigh(1, 100000)
    >>> stats.jarque_bera(x)
    (4.7165707989581342, 0.09458225503041906)
    >>> stats.jarque_bera(y)
    (6713.7098548143422, 0.0)

    """
    x = np.asarray(x)
    n = float(x.size)
    if n == 0:
        raise ValueError('At least one observation is required.')

    mu = x.mean()
    diffx = x - mu
    skewness = (1 / n * np.sum(diffx**3)) / (1 / n * np.sum(diffx**2))**(3 / 2.)
    kurtosis = (1 / n * np.sum(diffx**4)) / (1 / n * np.sum(diffx**2))**2
    jb_value = n / 6 * (skewness**2 + (kurtosis - 3)**2 / 4)
    p = 1 - distributions.chi2.cdf(jb_value, 2)

    return jb_value, p


#####################################
######  FREQUENCY FUNCTIONS  #######
#####################################

def itemfreq(a):
    """
    Returns a 2-D array of item frequencies.

    Parameters
    ----------
    a : (N,) array_like
        Input array.

    Returns
    -------
    itemfreq : (K, 2) ndarray
        A 2-D frequency table.  Column 1 contains sorted, unique values from
        `a`, column 2 contains their respective counts.

    Examples
    --------
    >>> a = np.array([1, 1, 5, 0, 1, 2, 2, 0, 1, 4])
    >>> stats.itemfreq(a)
    array([[ 0.,  2.],
           [ 1.,  4.],
           [ 2.,  2.],
           [ 4.,  1.],
           [ 5.,  1.]])
    >>> np.bincount(a)
    array([2, 4, 2, 0, 1, 1])

    >>> stats.itemfreq(a/10.)
    array([[ 0. ,  2. ],
           [ 0.1,  4. ],
           [ 0.2,  2. ],
           [ 0.4,  1. ],
           [ 0.5,  1. ]])

    """
    items, inv = np.unique(a, return_inverse=True)
    freq = np.bincount(inv)
    return np.array([items, freq]).T


def scoreatpercentile(a, per, limit=(), interpolation_method='fraction',
                      axis=None):
    """
    Calculate the score at a given percentile of the input sequence.

    For example, the score at `per=50` is the median. If the desired quantile
    lies between two data points, we interpolate between them, according to
    the value of `interpolation`. If the parameter `limit` is provided, it
    should be a tuple (lower, upper) of two values.

    Parameters
    ----------
    a : array_like
        A 1-D array of values from which to extract score.
    per : array_like
        Percentile(s) at which to extract score.  Values should be in range
        [0,100].
    limit : tuple, optional
        Tuple of two scalars, the lower and upper limits within which to
        compute the percentile. Values of `a` outside
        this (closed) interval will be ignored.
    interpolation : {'fraction', 'lower', 'higher'}, optional
        This optional parameter specifies the interpolation method to use,
        when the desired quantile lies between two data points `i` and `j`

          - fraction: ``i + (j - i) * fraction`` where ``fraction`` is the
            fractional part of the index surrounded by ``i`` and ``j``.
          - lower: ``i``.
          - higher: ``j``.

    axis : int, optional
        Axis along which the percentiles are computed. The default (None)
        is to compute the median along a flattened version of the array.

    Returns
    -------
    score : float or ndarray
        Score at percentile(s).

    See Also
    --------
    percentileofscore, numpy.percentile

    Notes
    -----
    This function will become obsolete in the future.
    For Numpy 1.9 and higher, `numpy.percentile` provides all the functionality
    that `scoreatpercentile` provides.  And it's significantly faster.
    Therefore it's recommended to use `numpy.percentile` for users that have
    numpy >= 1.9.

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.arange(100)
    >>> stats.scoreatpercentile(a, 50)
    49.5

    """
    # adapted from NumPy's percentile function.  When we require numpy >= 1.8,
    # the implementation of this function can be replaced by np.percentile.
    a = np.asarray(a)
    if a.size == 0:
        # empty array, return nan(s) with shape matching `per`
        if np.isscalar(per):
            return np.nan
        else:
            return np.ones(np.asarray(per).shape, dtype=np.float64) * np.nan

    if limit:
        a = a[(limit[0] <= a) & (a <= limit[1])]

    sorted = np.sort(a, axis=axis)
    if axis is None:
        axis = 0

    return _compute_qth_percentile(sorted, per, interpolation_method, axis)


# handle sequence of per's without calling sort multiple times
def _compute_qth_percentile(sorted, per, interpolation_method, axis):
    if not np.isscalar(per):
        score = [_compute_qth_percentile(sorted, i, interpolation_method, axis)
                 for i in per]
        return np.array(score)

    if (per < 0) or (per > 100):
        raise ValueError("percentile must be in the range [0, 100]")

    indexer = [slice(None)] * sorted.ndim
    idx = per / 100. * (sorted.shape[axis] - 1)

    if int(idx) != idx:
        # round fractional indices according to interpolation method
        if interpolation_method == 'lower':
            idx = int(np.floor(idx))
        elif interpolation_method == 'higher':
            idx = int(np.ceil(idx))
        elif interpolation_method == 'fraction':
            pass  # keep idx as fraction and interpolate
        else:
            raise ValueError("interpolation_method can only be 'fraction', "
                             "'lower' or 'higher'")

    i = int(idx)
    if i == idx:
        indexer[axis] = slice(i, i + 1)
        weights = array(1)
        sumval = 1.0
    else:
        indexer[axis] = slice(i, i + 2)
        j = i + 1
        weights = array([(j - idx), (idx - i)], float)
        wshape = [1] * sorted.ndim
        wshape[axis] = 2
        weights.shape = wshape
        sumval = weights.sum()

    # Use np.add.reduce (== np.sum but a little faster) to coerce data type
    return np.add.reduce(sorted[indexer] * weights, axis=axis) / sumval


def percentileofscore(a, score, kind='rank'):
    """
    The percentile rank of a score relative to a list of scores.

    A `percentileofscore` of, for example, 80% means that 80% of the
    scores in `a` are below the given score. In the case of gaps or
    ties, the exact definition depends on the optional keyword, `kind`.

    Parameters
    ----------
    a : array_like
        Array of scores to which `score` is compared.
    score : int or float
        Score that is compared to the elements in `a`.
    kind : {'rank', 'weak', 'strict', 'mean'}, optional
        This optional parameter specifies the interpretation of the
        resulting score:

        - "rank": Average percentage ranking of score.  In case of
                  multiple matches, average the percentage rankings of
                  all matching scores.
        - "weak": This kind corresponds to the definition of a cumulative
                  distribution function.  A percentileofscore of 80%
                  means that 80% of values are less than or equal
                  to the provided score.
        - "strict": Similar to "weak", except that only values that are
                    strictly less than the given score are counted.
        - "mean": The average of the "weak" and "strict" scores, often used in
                  testing.  See

                  http://en.wikipedia.org/wiki/Percentile_rank

    Returns
    -------
    pcos : float
        Percentile-position of score (0-100) relative to `a`.

    Examples
    --------
    Three-quarters of the given values lie below a given score:

    >>> percentileofscore([1, 2, 3, 4], 3)
    75.0

    With multiple matches, note how the scores of the two matches, 0.6
    and 0.8 respectively, are averaged:

    >>> percentileofscore([1, 2, 3, 3, 4], 3)
    70.0

    Only 2/5 values are strictly less than 3:

    >>> percentileofscore([1, 2, 3, 3, 4], 3, kind='strict')
    40.0

    But 4/5 values are less than or equal to 3:

    >>> percentileofscore([1, 2, 3, 3, 4], 3, kind='weak')
    80.0

    The average between the weak and the strict scores is

    >>> percentileofscore([1, 2, 3, 3, 4], 3, kind='mean')
    60.0

    """
    a = np.array(a)
    n = len(a)

    if kind == 'rank':
        if not(np.any(a == score)):
            a = np.append(a, score)
            a_len = np.array(list(range(len(a))))
        else:
            a_len = np.array(list(range(len(a)))) + 1.0

        a = np.sort(a)
        idx = [a == score]
        pct = (np.mean(a_len[idx]) / n) * 100.0
        return pct

    elif kind == 'strict':
        return sum(a < score) / float(n) * 100
    elif kind == 'weak':
        return sum(a <= score) / float(n) * 100
    elif kind == 'mean':
        return (sum(a < score) + sum(a <= score)) * 50 / float(n)
    else:
        raise ValueError("kind can only be 'rank', 'strict', 'weak' or 'mean'")


def histogram2(a, bins):
    """
    Compute histogram using divisions in bins.

    Count the number of times values from array `a` fall into
    numerical ranges defined by `bins`.  Range x is given by
    bins[x] <= range_x < bins[x+1] where x =0,N and N is the
    length of the `bins` array.  The last range is given by
    bins[N] <= range_N < infinity.  Values less than bins[0] are
    not included in the histogram.

    Parameters
    ----------
    a : array_like of rank 1
        The array of values to be assigned into bins
    bins : array_like of rank 1
        Defines the ranges of values to use during histogramming.

    Returns
    -------
    histogram2 : ndarray of rank 1
        Each value represents the occurrences for a given bin (range) of
        values.

    """
    # comment: probably obsoleted by numpy.histogram()
    n = np.searchsorted(np.sort(a), bins)
    n = np.concatenate([n, [len(a)]])
    return n[1:]-n[:-1]


def histogram(a, numbins=10, defaultlimits=None, weights=None, printextras=False):
    """
    Separates the range into several bins and returns the number of instances
    in each bin.

    Parameters
    ----------
    a : array_like
        Array of scores which will be put into bins.
    numbins : int, optional
        The number of bins to use for the histogram. Default is 10.
    defaultlimits : tuple (lower, upper), optional
        The lower and upper values for the range of the histogram.
        If no value is given, a range slightly larger then the range of the
        values in a is used. Specifically ``(a.min() - s, a.max() + s)``,
        where ``s = (1/2)(a.max() - a.min()) / (numbins - 1)``.
    weights : array_like, optional
        The weights for each value in `a`. Default is None, which gives each
        value a weight of 1.0
    printextras : bool, optional
        If True, if there are extra points (i.e. the points that fall outside
        the bin limits) a warning is raised saying how many of those points
        there are.  Default is False.

    Returns
    -------
    histogram : ndarray
        Number of points (or sum of weights) in each bin.
    low_range : float
        Lowest value of histogram, the lower limit of the first bin.
    binsize : float
        The size of the bins (all bins have the same size).
    extrapoints : int
        The number of points outside the range of the histogram.

    See Also
    --------
    numpy.histogram

    Notes
    -----
    This histogram is based on numpy's histogram but has a larger range by
    default if default limits is not set.

    """
    a = np.ravel(a)
    if defaultlimits is None:
        # no range given, so use values in `a`
        data_min = a.min()
        data_max = a.max()
        # Have bins extend past min and max values slightly
        s = (data_max - data_min) / (2. * (numbins - 1.))
        defaultlimits = (data_min - s, data_max + s)
    # use numpy's histogram method to compute bins
    hist, bin_edges = np.histogram(a, bins=numbins, range=defaultlimits,
                                   weights=weights)
    # hist are not always floats, convert to keep with old output
    hist = np.array(hist, dtype=float)
    # fixed width for bins is assumed, as numpy's histogram gives
    # fixed width bins for int values for 'bins'
    binsize = bin_edges[1] - bin_edges[0]
    # calculate number of extra points
    extrapoints = len([v for v in a
                       if defaultlimits[0] > v or v > defaultlimits[1]])
    if extrapoints > 0 and printextras:
        warnings.warn("Points outside given histogram range = %s"
                      % extrapoints)
    return (hist, defaultlimits[0], binsize, extrapoints)


def cumfreq(a, numbins=10, defaultreallimits=None, weights=None):
    """
    Returns a cumulative frequency histogram, using the histogram function.

    Parameters
    ----------
    a : array_like
        Input array.
    numbins : int, optional
        The number of bins to use for the histogram. Default is 10.
    defaultlimits : tuple (lower, upper), optional
        The lower and upper values for the range of the histogram.
        If no value is given, a range slightly larger than the range of the
        values in `a` is used. Specifically ``(a.min() - s, a.max() + s)``,
        where ``s = (1/2)(a.max() - a.min()) / (numbins - 1)``.
    weights : array_like, optional
        The weights for each value in `a`. Default is None, which gives each
        value a weight of 1.0

    Returns
    -------
    cumfreq : ndarray
        Binned values of cumulative frequency.
    lowerreallimit : float
        Lower real limit
    binsize : float
        Width of each bin.
    extrapoints : int
        Extra points.

    Examples
    --------
    >>> import scipy.stats as stats
    >>> x = [1, 4, 2, 1, 3, 1]
    >>> cumfreqs, lowlim, binsize, extrapoints = stats.cumfreq(x, numbins=4)
    >>> cumfreqs
    array([ 3.,  4.,  5.,  6.])
    >>> cumfreqs, lowlim, binsize, extrapoints = \
    ...     stats.cumfreq(x, numbins=4, defaultreallimits=(1.5, 5))
    >>> cumfreqs
    array([ 1.,  2.,  3.,  3.])
    >>> extrapoints
    3

    """
    h,l,b,e = histogram(a, numbins, defaultreallimits, weights=weights)
    cumhist = np.cumsum(h*1, axis=0)
    return cumhist,l,b,e


def relfreq(a, numbins=10, defaultreallimits=None, weights=None):
    """
    Returns a relative frequency histogram, using the histogram function.

    Parameters
    ----------
    a : array_like
        Input array.
    numbins : int, optional
        The number of bins to use for the histogram. Default is 10.
    defaultreallimits : tuple (lower, upper), optional
        The lower and upper values for the range of the histogram.
        If no value is given, a range slightly larger then the range of the
        values in a is used. Specifically ``(a.min() - s, a.max() + s)``,
        where ``s = (1/2)(a.max() - a.min()) / (numbins - 1)``.
    weights : array_like, optional
        The weights for each value in `a`. Default is None, which gives each
        value a weight of 1.0

    Returns
    -------
    relfreq : ndarray
        Binned values of relative frequency.
    lowerreallimit : float
        Lower real limit
    binsize : float
        Width of each bin.
    extrapoints : int
        Extra points.

    Examples
    --------
    >>> import scipy.stats as stats
    >>> a = np.array([1, 4, 2, 1, 3, 1])
    >>> relfreqs, lowlim, binsize, extrapoints = stats.relfreq(a, numbins=4)
    >>> relfreqs
    array([ 0.5       ,  0.16666667,  0.16666667,  0.16666667])
    >>> np.sum(relfreqs)  # relative frequencies should add up to 1
    0.99999999999999989

    """
    h, l, b, e = histogram(a, numbins, defaultreallimits, weights=weights)
    h = np.array(h / float(np.array(a).shape[0]))
    return h, l, b, e


#####################################
######  VARIABILITY FUNCTIONS  #####
#####################################

def obrientransform(*args):
    """
    Computes the O'Brien transform on input data (any number of arrays).

    Used to test for homogeneity of variance prior to running one-way stats.
    Each array in ``*args`` is one level of a factor.
    If `f_oneway` is run on the transformed data and found significant,
    the variances are unequal.  From Maxwell and Delaney [1]_, p.112.

    Parameters
    ----------
    args : tuple of array_like
        Any number of arrays.

    Returns
    -------
    obrientransform : ndarray
        Transformed data for use in an ANOVA.  The first dimension
        of the result corresponds to the sequence of transformed
        arrays.  If the arrays given are all 1-D of the same length,
        the return value is a 2-D array; otherwise it is a 1-D array
        of type object, with each element being an ndarray.

    References
    ----------
    .. [1] S. E. Maxwell and H. D. Delaney, "Designing Experiments and
           Analyzing Data: A Model Comparison Perspective", Wadsworth, 1990.

    Examples
    --------
    We'll test the following data sets for differences in their variance.

    >>> x = [10, 11, 13, 9, 7, 12, 12, 9, 10]
    >>> y = [13, 21, 5, 10, 8, 14, 10, 12, 7, 15]

    Apply the O'Brien transform to the data.

    >>> tx, ty = obrientransform(x, y)

    Use `scipy.stats.f_oneway` to apply a one-way ANOVA test to the
    transformed data.

    >>> from scipy.stats import f_oneway
    >>> F, p = f_oneway(tx, ty)
    >>> p
    0.1314139477040335

    If we require that ``p < 0.05`` for significance, we cannot conclude
    that the variances are different.
    """
    TINY = np.sqrt(np.finfo(float).eps)

    # `arrays` will hold the transformed arguments.
    arrays = []

    for arg in args:
        a = np.asarray(arg)
        n = len(a)
        mu = np.mean(a)
        sq = (a - mu)**2
        sumsq = sq.sum()

        # The O'Brien transform.
        t = ((n - 1.5) * n * sq - 0.5 * sumsq) / ((n - 1) * (n - 2))

        # Check that the mean of the transformed data is equal to the
        # original variance.
        var = sumsq / (n - 1)
        if abs(var - np.mean(t)) > TINY:
            raise ValueError('Lack of convergence in obrientransform.')

        arrays.append(t)

    # If the arrays are not all the same shape, calling np.array(arrays)
    # creates a 1-D array with dtype `object` in numpy 1.6+. In numpy
    # 1.5.x, it raises an exception.  To work around this, we explicitly
    # set the dtype to `object` when the arrays are not all the same shape.
    if len(arrays) < 2 or all(x.shape == arrays[0].shape for x in arrays[1:]):
        dt = None
    else:
        dt = object
    return np.array(arrays, dtype=dt)


def signaltonoise(a, axis=0, ddof=0):
    """
    The signal-to-noise ratio of the input data.

    Returns the signal-to-noise ratio of `a`, here defined as the mean
    divided by the standard deviation.

    Parameters
    ----------
    a : array_like
        An array_like object containing the sample data.
    axis : int or None, optional
        If axis is equal to None, the array is first ravel'd. If axis is an
        integer, this is the axis over which to operate. Default is 0.
    ddof : int, optional
        Degrees of freedom correction for standard deviation. Default is 0.

    Returns
    -------
    s2n : ndarray
        The mean to standard deviation ratio(s) along `axis`, or 0 where the
        standard deviation is 0.

    """
    a = np.asanyarray(a)
    m = a.mean(axis)
    sd = a.std(axis=axis, ddof=ddof)
    return np.where(sd == 0, 0, m/sd)


def sem(a, axis=0, ddof=1):
    """
    Calculates the standard error of the mean (or standard error of
    measurement) of the values in the input array.

    Parameters
    ----------
    a : array_like
        An array containing the values for which the standard error is
        returned.
    axis : int or None, optional.
        If axis is None, ravel `a` first. If axis is an integer, this will be
        the axis over which to operate. Defaults to 0.
    ddof : int, optional
        Delta degrees-of-freedom. How many degrees of freedom to adjust
        for bias in limited samples relative to the population estimate
        of variance. Defaults to 1.

    Returns
    -------
    s : ndarray or float
        The standard error of the mean in the sample(s), along the input axis.

    Notes
    -----
    The default value for `ddof` is different to the default (0) used by other
    ddof containing routines, such as np.std nd stats.nanstd.

    Examples
    --------
    Find standard error along the first axis:

    >>> from scipy import stats
    >>> a = np.arange(20).reshape(5,4)
    >>> stats.sem(a)
    array([ 2.8284,  2.8284,  2.8284,  2.8284])

    Find standard error across the whole array, using n degrees of freedom:

    >>> stats.sem(a, axis=None, ddof=0)
    1.2893796958227628

    """
    a, axis = _chk_asarray(a, axis)
    n = a.shape[axis]
    s = np.std(a, axis=axis, ddof=ddof) / np.sqrt(n)
    return s


def zscore(a, axis=0, ddof=0):
    """
    Calculates the z score of each value in the sample, relative to the sample
    mean and standard deviation.

    Parameters
    ----------
    a : array_like
        An array like object containing the sample data.
    axis : int or None, optional
        If `axis` is equal to None, the array is first raveled. If `axis` is
        an integer, this is the axis over which to operate. Default is 0.
    ddof : int, optional
        Degrees of freedom correction in the calculation of the
        standard deviation. Default is 0.

    Returns
    -------
    zscore : array_like
        The z-scores, standardized by mean and standard deviation of input
        array `a`.

    Notes
    -----
    This function preserves ndarray subclasses, and works also with
    matrices and masked arrays (it uses `asanyarray` instead of `asarray`
    for parameters).

    Examples
    --------
    >>> a = np.array([ 0.7972,  0.0767,  0.4383,  0.7866,  0.8091,  0.1954,
                       0.6307, 0.6599,  0.1065,  0.0508])
    >>> from scipy import stats
    >>> stats.zscore(a)
    array([ 1.1273, -1.247 , -0.0552,  1.0923,  1.1664, -0.8559,  0.5786,
            0.6748, -1.1488, -1.3324])

    Computing along a specified axis, using n-1 degrees of freedom (``ddof=1``)
    to calculate the standard deviation:

    >>> b = np.array([[ 0.3148,  0.0478,  0.6243,  0.4608],
                      [ 0.7149,  0.0775,  0.6072,  0.9656],
                      [ 0.6341,  0.1403,  0.9759,  0.4064],
                      [ 0.5918,  0.6948,  0.904 ,  0.3721],
                      [ 0.0921,  0.2481,  0.1188,  0.1366]])
    >>> stats.zscore(b, axis=1, ddof=1)
    array([[-0.19264823, -1.28415119,  1.07259584,  0.40420358],
           [ 0.33048416, -1.37380874,  0.04251374,  1.00081084],
           [ 0.26796377, -1.12598418,  1.23283094, -0.37481053],
           [-0.22095197,  0.24468594,  1.19042819, -1.21416216],
           [-0.82780366,  1.4457416 , -0.43867764, -0.1792603 ]])
    """
    a = np.asanyarray(a)
    mns = a.mean(axis=axis)
    sstd = a.std(axis=axis, ddof=ddof)
    if axis and mns.ndim < a.ndim:
        return ((a - np.expand_dims(mns, axis=axis)) /
                 np.expand_dims(sstd,axis=axis))
    else:
        return (a - mns) / sstd


def zmap(scores, compare, axis=0, ddof=0):
    """
    Calculates the relative z-scores.

    Returns an array of z-scores, i.e., scores that are standardized to zero
    mean and unit variance, where mean and variance are calculated from the
    comparison array.

    Parameters
    ----------
    scores : array_like
        The input for which z-scores are calculated.
    compare : array_like
        The input from which the mean and standard deviation of the
        normalization are taken; assumed to have the same dimension as
        `scores`.
    axis : int or None, optional
        Axis over which mean and variance of `compare` are calculated.
        Default is 0.
    ddof : int, optional
        Degrees of freedom correction in the calculation of the
        standard deviation. Default is 0.

    Returns
    -------
    zscore : array_like
        Z-scores, in the same shape as `scores`.

    Notes
    -----
    This function preserves ndarray subclasses, and works also with
    matrices and masked arrays (it uses `asanyarray` instead of `asarray`
    for parameters).

    Examples
    --------
    >>> a = [0.5, 2.0, 2.5, 3]
    >>> b = [0, 1, 2, 3, 4]
    >>> zmap(a, b)
    array([-1.06066017,  0.        ,  0.35355339,  0.70710678])
    """
    scores, compare = map(np.asanyarray, [scores, compare])
    mns = compare.mean(axis=axis)
    sstd = compare.std(axis=axis, ddof=ddof)
    if axis and mns.ndim < compare.ndim:
        return ((scores - np.expand_dims(mns, axis=axis)) /
                 np.expand_dims(sstd,axis=axis))
    else:
        return (scores - mns) / sstd


#####################################
#######  TRIMMING FUNCTIONS  #######
#####################################

def threshold(a, threshmin=None, threshmax=None, newval=0):
    """
    Clip array to a given value.

    Similar to numpy.clip(), except that values less than `threshmin` or
    greater than `threshmax` are replaced by `newval`, instead of by
    `threshmin` and `threshmax` respectively.

    Parameters
    ----------
    a : array_like
        Data to threshold.
    threshmin : float, int or None, optional
        Minimum threshold, defaults to None.
    threshmax : float, int or None, optional
        Maximum threshold, defaults to None.
    newval : float or int, optional
        Value to put in place of values in `a` outside of bounds.
        Defaults to 0.

    Returns
    -------
    out : ndarray
        The clipped input array, with values less than `threshmin` or
        greater than `threshmax` replaced with `newval`.

    Examples
    --------
    >>> a = np.array([9, 9, 6, 3, 1, 6, 1, 0, 0, 8])
    >>> from scipy import stats
    >>> stats.threshold(a, threshmin=2, threshmax=8, newval=-1)
    array([-1, -1,  6,  3, -1,  6, -1, -1, -1,  8])

    """
    a = asarray(a).copy()
    mask = zeros(a.shape, dtype=bool)
    if threshmin is not None:
        mask |= (a < threshmin)
    if threshmax is not None:
        mask |= (a > threshmax)
    a[mask] = newval
    return a


def sigmaclip(a, low=4., high=4.):
    """
    Iterative sigma-clipping of array elements.

    The output array contains only those elements of the input array `c`
    that satisfy the conditions ::

        mean(c) - std(c)*low < c < mean(c) + std(c)*high

    Starting from the full sample, all elements outside the critical range are
    removed. The iteration continues with a new critical range until no
    elements are outside the range.

    Parameters
    ----------
    a : array_like
        Data array, will be raveled if not 1-D.
    low : float, optional
        Lower bound factor of sigma clipping. Default is 4.
    high : float, optional
        Upper bound factor of sigma clipping. Default is 4.

    Returns
    -------
    c : ndarray
        Input array with clipped elements removed.
    critlower : float
        Lower threshold value use for clipping.
    critlupper : float
        Upper threshold value use for clipping.

    Examples
    --------
    >>> a = np.concatenate((np.linspace(9.5,10.5,31), np.linspace(0,20,5)))
    >>> fact = 1.5
    >>> c, low, upp = sigmaclip(a, fact, fact)
    >>> c
    array([  9.96666667,  10.        ,  10.03333333,  10.        ])
    >>> c.var(), c.std()
    (0.00055555555555555165, 0.023570226039551501)
    >>> low, c.mean() - fact*c.std(), c.min()
    (9.9646446609406727, 9.9646446609406727, 9.9666666666666668)
    >>> upp, c.mean() + fact*c.std(), c.max()
    (10.035355339059327, 10.035355339059327, 10.033333333333333)

    >>> a = np.concatenate((np.linspace(9.5,10.5,11),
        np.linspace(-100,-50,3)))
    >>> c, low, upp = sigmaclip(a, 1.8, 1.8)
    >>> (c == np.linspace(9.5,10.5,11)).all()
    True

    """
    c = np.asarray(a).ravel()
    delta = 1
    while delta:
        c_std = c.std()
        c_mean = c.mean()
        size = c.size
        critlower = c_mean - c_std*low
        critupper = c_mean + c_std*high
        c = c[(c > critlower) & (c < critupper)]
        delta = size-c.size
    return c, critlower, critupper


def trimboth(a, proportiontocut, axis=0):
    """
    Slices off a proportion of items from both ends of an array.

    Slices off the passed proportion of items from both ends of the passed
    array (i.e., with `proportiontocut` = 0.1, slices leftmost 10% **and**
    rightmost 10% of scores).  You must pre-sort the array if you want
    'proper' trimming.  Slices off less if proportion results in a
    non-integer slice index (i.e., conservatively slices off
    `proportiontocut`).

    Parameters
    ----------
    a : array_like
        Data to trim.
    proportiontocut : float
        Proportion (in range 0-1) of total data set to trim of each end.
    axis : int or None, optional
        Axis along which the observations are trimmed. The default is to trim
        along axis=0. If axis is None then the array will be flattened before
        trimming.

    Returns
    -------
    out : ndarray
        Trimmed version of array `a`.

    See Also
    --------
    trim_mean

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.arange(20)
    >>> b = stats.trimboth(a, 0.1)
    >>> b.shape
    (16,)

    """
    a = np.asarray(a)
    if axis is None:
        a = a.ravel()
        axis = 0

    nobs = a.shape[axis]
    lowercut = int(proportiontocut * nobs)
    uppercut = nobs - lowercut
    if (lowercut >= uppercut):
        raise ValueError("Proportion too big.")

    sl = [slice(None)] * a.ndim
    sl[axis] = slice(lowercut, uppercut)
    return a[sl]


def trim1(a, proportiontocut, tail='right'):
    """
    Slices off a proportion of items from ONE end of the passed array
    distribution.

    If `proportiontocut` = 0.1, slices off 'leftmost' or 'rightmost'
    10% of scores.  Slices off LESS if proportion results in a non-integer
    slice index (i.e., conservatively slices off `proportiontocut` ).

    Parameters
    ----------
    a : array_like
        Input array
    proportiontocut : float
        Fraction to cut off of 'left' or 'right' of distribution
    tail : {'left', 'right'}, optional
        Defaults to 'right'.

    Returns
    -------
    trim1 : ndarray
        Trimmed version of array `a`

    """
    a = asarray(a)
    if tail.lower() == 'right':
        lowercut = 0
        uppercut = len(a) - int(proportiontocut*len(a))
    elif tail.lower() == 'left':
        lowercut = int(proportiontocut*len(a))
        uppercut = len(a)

    return a[lowercut:uppercut]


def trim_mean(a, proportiontocut, axis=0):
    """
    Return mean of array after trimming distribution from both lower and upper
    tails.

    If `proportiontocut` = 0.1, slices off 'leftmost' and 'rightmost' 10% of
    scores. Slices off LESS if proportion results in a non-integer slice
    index (i.e., conservatively slices off `proportiontocut` ).

    Parameters
    ----------
    a : array_like
        Input array
    proportiontocut : float
        Fraction to cut off of both tails of the distribution
    axis : int or None, optional
        Axis along which the trimmed means are computed. The default is axis=0.
        If axis is None then the trimmed mean will be computed for the
        flattened array.

    Returns
    -------
    trim_mean : ndarray
        Mean of trimmed array.

    See Also
    --------
    trimboth

    Examples
    --------
    >>> from scipy import stats
    >>> x = np.arange(20)
    >>> stats.trim_mean(x, 0.1)
    9.5
    >>> x2 = x.reshape(5, 4)
    >>> x2
    array([[ 0,  1,  2,  3],
           [ 4,  5,  6,  7],
           [ 8,  9, 10, 11],
           [12, 13, 14, 15],
           [16, 17, 18, 19]])
    >>> stats.trim_mean(x2, 0.25)
    array([  8.,   9.,  10.,  11.])
    >>> stats.trim_mean(x2, 0.25, axis=1)
    array([  1.5,   5.5,   9.5,  13.5,  17.5])

    """
    a = np.asarray(a)
    if axis is None:
        nobs = a.size
    else:
        nobs = a.shape[axis]
    lowercut = int(proportiontocut * nobs)
    uppercut = nobs - lowercut - 1
    if (lowercut > uppercut):
        raise ValueError("Proportion too big.")

    try:
        atmp = np.partition(a, (lowercut, uppercut), axis)
    except AttributeError:
        atmp = np.sort(a, axis)

    newa = trimboth(atmp, proportiontocut, axis=axis)
    return np.mean(newa, axis=axis)


def f_oneway(*args):
    """
    Performs a 1-way ANOVA.

    The one-way ANOVA tests the null hypothesis that two or more groups have
    the same population mean.  The test is applied to samples from two or
    more groups, possibly with differing sizes.

    Parameters
    ----------
    sample1, sample2, ... : array_like
        The sample measurements for each group.

    Returns
    -------
    F-value : float
        The computed F-value of the test.
    p-value : float
        The associated p-value from the F-distribution.

    Notes
    -----
    The ANOVA test has important assumptions that must be satisfied in order
    for the associated p-value to be valid.

    1. The samples are independent.
    2. Each sample is from a normally distributed population.
    3. The population standard deviations of the groups are all equal.  This
       property is known as homoscedasticity.

    If these assumptions are not true for a given set of data, it may still be
    possible to use the Kruskal-Wallis H-test (`scipy.stats.kruskal`) although
    with some loss of power.

    The algorithm is from Heiman[2], pp.394-7.


    References
    ----------
    .. [1] Lowry, Richard.  "Concepts and Applications of Inferential
           Statistics". Chapter 14.
           http://faculty.vassar.edu/lowry/ch14pt1.html

    .. [2] Heiman, G.W.  Research Methods in Statistics. 2002.

    """
    args = [np.asarray(arg, dtype=float) for arg in args]
    na = len(args)    # ANOVA on 'na' groups, each in it's own array
    alldata = np.concatenate(args)
    bign = len(alldata)
    sstot = ss(alldata) - (square_of_sums(alldata) / float(bign))
    ssbn = 0
    for a in args:
        ssbn += square_of_sums(a) / float(len(a))

    ssbn -= (square_of_sums(alldata) / float(bign))
    sswn = sstot - ssbn
    dfbn = na - 1
    dfwn = bign - na
    msb = ssbn / float(dfbn)
    msw = sswn / float(dfwn)
    f = msb / msw
    prob = special.fdtrc(dfbn, dfwn, f)   # equivalent to stats.f.sf
    return f, prob


def pearsonr(x, y):
    """
    Calculates a Pearson correlation coefficient and the p-value for testing
    non-correlation.

    The Pearson correlation coefficient measures the linear relationship
    between two datasets. Strictly speaking, Pearson's correlation requires
    that each dataset be normally distributed. Like other correlation
    coefficients, this one varies between -1 and +1 with 0 implying no
    correlation. Correlations of -1 or +1 imply an exact linear
    relationship. Positive correlations imply that as x increases, so does
    y. Negative correlations imply that as x increases, y decreases.

    The p-value roughly indicates the probability of an uncorrelated system
    producing datasets that have a Pearson correlation at least as extreme
    as the one computed from these datasets. The p-values are not entirely
    reliable but are probably reasonable for datasets larger than 500 or so.

    Parameters
    ----------
    x : (N,) array_like
        Input
    y : (N,) array_like
        Input

    Returns
    -------
    (Pearson's correlation coefficient,
     2-tailed p-value)

    References
    ----------
    http://www.statsoft.com/textbook/glosp.html#Pearson%20Correlation

    """
    # x and y should have same length.
    x = np.asarray(x)
    y = np.asarray(y)
    n = len(x)
    mx = x.mean()
    my = y.mean()
    xm, ym = x-mx, y-my
    r_num = np.add.reduce(xm * ym)
    r_den = np.sqrt(ss(xm) * ss(ym))
    r = r_num / r_den

    # Presumably, if abs(r) > 1, then it is only some small artifact of floating
    # point arithmetic.
    r = max(min(r, 1.0), -1.0)
    df = n-2
    if abs(r) == 1.0:
        prob = 0.0
    else:
        t_squared = r*r * (df / ((1.0 - r) * (1.0 + r)))
        prob = betai(0.5*df, 0.5, df / (df + t_squared))
    return r, prob


def fisher_exact(table, alternative='two-sided'):
    """Performs a Fisher exact test on a 2x2 contingency table.

    Parameters
    ----------
    table : array_like of ints
        A 2x2 contingency table.  Elements should be non-negative integers.
    alternative : {'two-sided', 'less', 'greater'}, optional
        Which alternative hypothesis to the null hypothesis the test uses.
        Default is 'two-sided'.

    Returns
    -------
    oddsratio : float
        This is prior odds ratio and not a posterior estimate.
    p_value : float
        P-value, the probability of obtaining a distribution at least as
        extreme as the one that was actually observed, assuming that the
        null hypothesis is true.

    See Also
    --------
    chi2_contingency : Chi-square test of independence of variables in a
        contingency table.

    Notes
    -----
    The calculated odds ratio is different from the one R uses. In R language,
    this implementation returns the (more common) "unconditional Maximum
    Likelihood Estimate", while R uses the "conditional Maximum Likelihood
    Estimate".

    For tables with large numbers the (inexact) chi-square test implemented
    in the function `chi2_contingency` can also be used.

    Examples
    --------
    Say we spend a few days counting whales and sharks in the Atlantic and
    Indian oceans. In the Atlantic ocean we find 8 whales and 1 shark, in the
    Indian ocean 2 whales and 5 sharks. Then our contingency table is::

                Atlantic  Indian
        whales     8        2
        sharks     1        5

    We use this table to find the p-value:

    >>> oddsratio, pvalue = stats.fisher_exact([[8, 2], [1, 5]])
    >>> pvalue
    0.0349...

    The probability that we would observe this or an even more imbalanced ratio
    by chance is about 3.5%.  A commonly used significance level is 5%, if we
    adopt that we can therefore conclude that our observed imbalance is
    statistically significant; whales prefer the Atlantic while sharks prefer
    the Indian ocean.

    """
    hypergeom = distributions.hypergeom
    c = np.asarray(table, dtype=np.int64)  # int32 is not enough for the algorithm
    if not c.shape == (2, 2):
        raise ValueError("The input `table` must be of shape (2, 2).")

    if np.any(c < 0):
        raise ValueError("All values in `table` must be nonnegative.")

    if 0 in c.sum(axis=0) or 0 in c.sum(axis=1):
        # If both values in a row or column are zero, the p-value is 1 and
        # the odds ratio is NaN.
        return np.nan, 1.0

    if c[1,0] > 0 and c[0,1] > 0:
        oddsratio = c[0,0] * c[1,1] / float(c[1,0] * c[0,1])
    else:
        oddsratio = np.inf

    n1 = c[0,0] + c[0,1]
    n2 = c[1,0] + c[1,1]
    n = c[0,0] + c[1,0]

    def binary_search(n, n1, n2, side):
        """Binary search for where to begin lower/upper halves in two-sided
        test.
        """
        if side == "upper":
            minval = mode
            maxval = n
        else:
            minval = 0
            maxval = mode
        guess = -1
        while maxval - minval > 1:
            if maxval == minval + 1 and guess == minval:
                guess = maxval
            else:
                guess = (maxval + minval) // 2
            pguess = hypergeom.pmf(guess, n1 + n2, n1, n)
            if side == "upper":
                ng = guess - 1
            else:
                ng = guess + 1
            if pguess <= pexact and hypergeom.pmf(ng, n1 + n2, n1, n) > pexact:
                break
            elif pguess < pexact:
                maxval = guess
            else:
                minval = guess
        if guess == -1:
            guess = minval
        if side == "upper":
            while guess > 0 and hypergeom.pmf(guess, n1 + n2, n1, n) < pexact * epsilon:
                guess -= 1
            while hypergeom.pmf(guess, n1 + n2, n1, n) > pexact / epsilon:
                guess += 1
        else:
            while hypergeom.pmf(guess, n1 + n2, n1, n) < pexact * epsilon:
                guess += 1
            while guess > 0 and hypergeom.pmf(guess, n1 + n2, n1, n) > pexact / epsilon:
                guess -= 1
        return guess

    if alternative == 'less':
        pvalue = hypergeom.cdf(c[0,0], n1 + n2, n1, n)
    elif alternative == 'greater':
        # Same formula as the 'less' case, but with the second column.
        pvalue = hypergeom.cdf(c[0,1], n1 + n2, n1, c[0,1] + c[1,1])
    elif alternative == 'two-sided':
        mode = int(float((n + 1) * (n1 + 1)) / (n1 + n2 + 2))
        pexact = hypergeom.pmf(c[0,0], n1 + n2, n1, n)
        pmode = hypergeom.pmf(mode, n1 + n2, n1, n)

        epsilon = 1 - 1e-4
        if np.abs(pexact - pmode) / np.maximum(pexact, pmode) <= 1 - epsilon:
            return oddsratio, 1.

        elif c[0,0] < mode:
            plower = hypergeom.cdf(c[0,0], n1 + n2, n1, n)
            if hypergeom.pmf(n, n1 + n2, n1, n) > pexact / epsilon:
                return oddsratio, plower

            guess = binary_search(n, n1, n2, "upper")
            pvalue = plower + hypergeom.sf(guess - 1, n1 + n2, n1, n)
        else:
            pupper = hypergeom.sf(c[0,0] - 1, n1 + n2, n1, n)
            if hypergeom.pmf(0, n1 + n2, n1, n) > pexact / epsilon:
                return oddsratio, pupper

            guess = binary_search(n, n1, n2, "lower")
            pvalue = pupper + hypergeom.cdf(guess, n1 + n2, n1, n)
    else:
        msg = "`alternative` should be one of {'two-sided', 'less', 'greater'}"
        raise ValueError(msg)

    if pvalue > 1.0:
        pvalue = 1.0
    return oddsratio, pvalue


def spearmanr(a, b=None, axis=0):
    """
    Calculates a Spearman rank-order correlation coefficient and the p-value
    to test for non-correlation.

    The Spearman correlation is a nonparametric measure of the monotonicity
    of the relationship between two datasets. Unlike the Pearson correlation,
    the Spearman correlation does not assume that both datasets are normally
    distributed. Like other correlation coefficients, this one varies
    between -1 and +1 with 0 implying no correlation. Correlations of -1 or
    +1 imply an exact monotonic relationship. Positive correlations imply that
    as x increases, so does y. Negative correlations imply that as x
    increases, y decreases.

    The p-value roughly indicates the probability of an uncorrelated system
    producing datasets that have a Spearman correlation at least as extreme
    as the one computed from these datasets. The p-values are not entirely
    reliable but are probably reasonable for datasets larger than 500 or so.

    Parameters
    ----------
    a, b : 1D or 2D array_like, b is optional
        One or two 1-D or 2-D arrays containing multiple variables and
        observations. Each column of `a` and `b` represents a variable, and
        each row entry a single observation of those variables. See also
        `axis`. Both arrays need to have the same length in the `axis`
        dimension.
    axis : int or None, optional
        If axis=0 (default), then each column represents a variable, with
        observations in the rows. If axis=0, the relationship is transposed:
        each row represents a variable, while the columns contain observations.
        If axis=None, then both arrays will be raveled.

    Returns
    -------
    rho : float or ndarray (2-D square)
        Spearman correlation matrix or correlation coefficient (if only 2
        variables are given as parameters. Correlation matrix is square with
        length equal to total number of variables (columns or rows) in a and b
        combined.
    p-value : float
        The two-sided p-value for a hypothesis test whose null hypothesis is
        that two sets of data are uncorrelated, has same dimension as rho.

    Notes
    -----
    Changes in scipy 0.8.0: rewrite to add tie-handling, and axis.

    References
    ----------
    [CRCProbStat2000]_ Section  14.7

    .. [CRCProbStat2000] Zwillinger, D. and Kokoska, S. (2000). CRC Standard
       Probability and Statistics Tables and Formulae. Chapman & Hall: New
       York. 2000.

    Examples
    --------
    >>> spearmanr([1,2,3,4,5],[5,6,7,8,7])
    (0.82078268166812329, 0.088587005313543798)
    >>> np.random.seed(1234321)
    >>> x2n=np.random.randn(100,2)
    >>> y2n=np.random.randn(100,2)
    >>> spearmanr(x2n)
    (0.059969996999699973, 0.55338590803773591)
    >>> spearmanr(x2n[:,0], x2n[:,1])
    (0.059969996999699973, 0.55338590803773591)
    >>> rho, pval = spearmanr(x2n,y2n)
    >>> rho
    array([[ 1.        ,  0.05997   ,  0.18569457,  0.06258626],
           [ 0.05997   ,  1.        ,  0.110003  ,  0.02534653],
           [ 0.18569457,  0.110003  ,  1.        ,  0.03488749],
           [ 0.06258626,  0.02534653,  0.03488749,  1.        ]])
    >>> pval
    array([[ 0.        ,  0.55338591,  0.06435364,  0.53617935],
           [ 0.55338591,  0.        ,  0.27592895,  0.80234077],
           [ 0.06435364,  0.27592895,  0.        ,  0.73039992],
           [ 0.53617935,  0.80234077,  0.73039992,  0.        ]])
    >>> rho, pval = spearmanr(x2n.T, y2n.T, axis=1)
    >>> rho
    array([[ 1.        ,  0.05997   ,  0.18569457,  0.06258626],
           [ 0.05997   ,  1.        ,  0.110003  ,  0.02534653],
           [ 0.18569457,  0.110003  ,  1.        ,  0.03488749],
           [ 0.06258626,  0.02534653,  0.03488749,  1.        ]])
    >>> spearmanr(x2n, y2n, axis=None)
    (0.10816770419260482, 0.1273562188027364)
    >>> spearmanr(x2n.ravel(), y2n.ravel())
    (0.10816770419260482, 0.1273562188027364)

    >>> xint = np.random.randint(10,size=(100,2))
    >>> spearmanr(xint)
    (0.052760927029710199, 0.60213045837062351)

    """
    a, axisout = _chk_asarray(a, axis)
    ar = np.apply_along_axis(rankdata,axisout,a)

    br = None
    if b is not None:
        b, axisout = _chk_asarray(b, axis)
        br = np.apply_along_axis(rankdata,axisout,b)
    n = a.shape[axisout]
    rs = np.corrcoef(ar,br,rowvar=axisout)

    olderr = np.seterr(divide='ignore')  # rs can have elements equal to 1
    try:
        t = rs * np.sqrt((n-2) / ((rs+1.0)*(1.0-rs)))
    finally:
        np.seterr(**olderr)
    prob = distributions.t.sf(np.abs(t),n-2)*2

    if rs.shape == (2,2):
        return rs[1,0], prob[1,0]
    else:
        return rs, prob


def pointbiserialr(x, y):
    """Calculates a point biserial correlation coefficient and the associated
    p-value.

    The point biserial correlation is used to measure the relationship
    between a binary variable, x, and a continuous variable, y. Like other
    correlation coefficients, this one varies between -1 and +1 with 0
    implying no correlation. Correlations of -1 or +1 imply a determinative
    relationship.

    This function uses a shortcut formula but produces the same result as
    `pearsonr`.

    Parameters
    ----------
    x : array_like of bools
        Input array.
    y : array_like
        Input array.

    Returns
    -------
    r : float
        R value
    p-value : float
        2-tailed p-value

    References
    ----------
    http://en.wikipedia.org/wiki/Point-biserial_correlation_coefficient

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.array([0, 0, 0, 1, 1, 1, 1])
    >>> b = np.arange(7)
    >>> stats.pointbiserialr(a, b)
    (0.8660254037844386, 0.011724811003954652)
    >>> stats.pearsonr(a, b)
    (0.86602540378443871, 0.011724811003954626)
    >>> np.corrcoef(a, b)
    array([[ 1.       ,  0.8660254],
           [ 0.8660254,  1.       ]])

    """
    x = np.asarray(x, dtype=bool)
    y = np.asarray(y, dtype=float)
    n = len(x)

    # phat is the fraction of x values that are True
    phat = x.sum() / float(len(x))
    y0 = y[~x]  # y-values where x is False
    y1 = y[x]  # y-values where x is True
    y0m = y0.mean()
    y1m = y1.mean()

    # phat - phat**2 is more stable than phat*(1-phat)
    rpb = (y1m - y0m) * np.sqrt(phat - phat**2) / y.std()

    df = n-2
    # fixme: see comment about TINY in pearsonr()
    TINY = 1e-20
    t = rpb*np.sqrt(df/((1.0-rpb+TINY)*(1.0+rpb+TINY)))
    prob = betai(0.5*df, 0.5, df/(df+t*t))
    return rpb, prob


def kendalltau(x, y, initial_lexsort=True):
    """
    Calculates Kendall's tau, a correlation measure for ordinal data.

    Kendall's tau is a measure of the correspondence between two rankings.
    Values close to 1 indicate strong agreement, values close to -1 indicate
    strong disagreement.  This is the tau-b version of Kendall's tau which
    accounts for ties.

    Parameters
    ----------
    x, y : array_like
        Arrays of rankings, of the same shape. If arrays are not 1-D, they will
        be flattened to 1-D.
    initial_lexsort : bool, optional
        Whether to use lexsort or quicksort as the sorting method for the
        initial sort of the inputs. Default is lexsort (True), for which
        `kendalltau` is of complexity O(n log(n)). If False, the complexity is
        O(n^2), but with a smaller pre-factor (so quicksort may be faster for
        small arrays).

    Returns
    -------
    Kendall's tau : float
       The tau statistic.
    p-value : float
       The two-sided p-value for a hypothesis test whose null hypothesis is
       an absence of association, tau = 0.

    Notes
    -----
    The definition of Kendall's tau that is used is::

      tau = (P - Q) / sqrt((P + Q + T) * (P + Q + U))

    where P is the number of concordant pairs, Q the number of discordant
    pairs, T the number of ties only in `x`, and U the number of ties only in
    `y`.  If a tie occurs for the same pair in both `x` and `y`, it is not
    added to either T or U.

    References
    ----------
    W.R. Knight, "A Computer Method for Calculating Kendall's Tau with
    Ungrouped Data", Journal of the American Statistical Association, Vol. 61,
    No. 314, Part 1, pp. 436-439, 1966.

    Examples
    --------
    >>> import scipy.stats as stats
    >>> x1 = [12, 2, 1, 12, 2]
    >>> x2 = [1, 4, 7, 1, 0]
    >>> tau, p_value = stats.kendalltau(x1, x2)
    >>> tau
    -0.47140452079103173
    >>> p_value
    0.24821309157521476

    """

    x = np.asarray(x).ravel()
    y = np.asarray(y).ravel()

    if not x.size or not y.size:
        return (np.nan, np.nan)  # Return NaN if arrays are empty

    n = np.int64(len(x))
    temp = list(range(n))  # support structure used by mergesort
    # this closure recursively sorts sections of perm[] by comparing
    # elements of y[perm[]] using temp[] as support
    # returns the number of swaps required by an equivalent bubble sort

    def mergesort(offs, length):
        exchcnt = 0
        if length == 1:
            return 0
        if length == 2:
            if y[perm[offs]] <= y[perm[offs+1]]:
                return 0
            t = perm[offs]
            perm[offs] = perm[offs+1]
            perm[offs+1] = t
            return 1
        length0 = length // 2
        length1 = length - length0
        middle = offs + length0
        exchcnt += mergesort(offs, length0)
        exchcnt += mergesort(middle, length1)
        if y[perm[middle - 1]] < y[perm[middle]]:
            return exchcnt
        # merging
        i = j = k = 0
        while j < length0 or k < length1:
            if k >= length1 or (j < length0 and y[perm[offs + j]] <=
                                                y[perm[middle + k]]):
                temp[i] = perm[offs + j]
                d = i - j
                j += 1
            else:
                temp[i] = perm[middle + k]
                d = (offs + i) - (middle + k)
                k += 1
            if d > 0:
                exchcnt += d
            i += 1
        perm[offs:offs+length] = temp[0:length]
        return exchcnt

    # initial sort on values of x and, if tied, on values of y
    if initial_lexsort:
        # sort implemented as mergesort, worst case: O(n log(n))
        perm = np.lexsort((y, x))
    else:
        # sort implemented as quicksort, 30% faster but with worst case: O(n^2)
        perm = list(range(n))
        perm.sort(key=lambda a: (x[a], y[a]))

    # compute joint ties
    first = 0
    t = 0
    for i in xrange(1, n):
        if x[perm[first]] != x[perm[i]] or y[perm[first]] != y[perm[i]]:
            t += ((i - first) * (i - first - 1)) // 2
            first = i
    t += ((n - first) * (n - first - 1)) // 2

    # compute ties in x
    first = 0
    u = 0
    for i in xrange(1,n):
        if x[perm[first]] != x[perm[i]]:
            u += ((i - first) * (i - first - 1)) // 2
            first = i
    u += ((n - first) * (n - first - 1)) // 2

    # count exchanges
    exchanges = mergesort(0, n)
    # compute ties in y after mergesort with counting
    first = 0
    v = 0
    for i in xrange(1,n):
        if y[perm[first]] != y[perm[i]]:
            v += ((i - first) * (i - first - 1)) // 2
            first = i
    v += ((n - first) * (n - first - 1)) // 2

    tot = (n * (n - 1)) // 2
    if tot == u or tot == v:
        return (np.nan, np.nan)    # Special case for all ties in both ranks

    # Prevent overflow; equal to np.sqrt((tot - u) * (tot - v))
    denom = np.exp(0.5 * (np.log(tot - u) + np.log(tot - v)))
    tau = ((tot - (v + u - t)) - 2.0 * exchanges) / denom

    # what follows reproduces the ending of Gary Strangman's original
    # stats.kendalltau() in SciPy
    svar = (4.0 * n + 10.0) / (9.0 * n * (n - 1))
    z = tau / np.sqrt(svar)
    prob = special.erfc(np.abs(z) / 1.4142136)

    return tau, prob


def linregress(x, y=None):
    """
    Calculate a regression line

    This computes a least-squares regression for two sets of measurements.

    Parameters
    ----------
    x, y : array_like
        two sets of measurements.  Both arrays should have the same length.
        If only x is given (and y=None), then it must be a two-dimensional
        array where one dimension has length 2.  The two sets of measurements
        are then found by splitting the array along the length-2 dimension.

    Returns
    -------
    slope : float
        slope of the regression line
    intercept : float
        intercept of the regression line
    r-value : float
        correlation coefficient
    p-value : float
        two-sided p-value for a hypothesis test whose null hypothesis is
        that the slope is zero.
    stderr : float
        Standard error of the estimate


    Examples
    --------
    >>> from scipy import stats
    >>> import numpy as np
    >>> x = np.random.random(10)
    >>> y = np.random.random(10)
    >>> slope, intercept, r_value, p_value, std_err = stats.linregress(x,y)

    # To get coefficient of determination (r_squared)

    >>> print "r-squared:", r_value**2
    r-squared: 0.15286643777

    """
    TINY = 1.0e-20
    if y is None:  # x is a (2, N) or (N, 2) shaped array_like
        x = asarray(x)
        if x.shape[0] == 2:
            x, y = x
        elif x.shape[1] == 2:
            x, y = x.T
        else:
            msg = "If only `x` is given as input, it has to be of shape (2, N) \
            or (N, 2), provided shape was %s" % str(x.shape)
            raise ValueError(msg)
    else:
        x = asarray(x)
        y = asarray(y)
    n = len(x)
    xmean = np.mean(x,None)
    ymean = np.mean(y,None)

    # average sum of squares:
    ssxm, ssxym, ssyxm, ssym = np.cov(x, y, bias=1).flat
    r_num = ssxym
    r_den = np.sqrt(ssxm*ssym)
    if r_den == 0.0:
        r = 0.0
    else:
        r = r_num / r_den
        # test for numerical error propagation
        if (r > 1.0):
            r = 1.0
        elif (r < -1.0):
            r = -1.0

    df = n-2
    t = r*np.sqrt(df/((1.0-r+TINY)*(1.0+r+TINY)))
    prob = distributions.t.sf(np.abs(t),df)*2
    slope = r_num / ssxm
    intercept = ymean - slope*xmean
    sterrest = np.sqrt((1-r*r)*ssym / ssxm / df)
    return slope, intercept, r, prob, sterrest


def theilslopes(y, x=None, alpha=0.95):
    r"""
    Computes the Theil-Sen estimator for a set of points (x, y).

    `theilslopes` implements a method for robust linear regression.  It
    computes the slope as the median of all slopes between paired values.

    Parameters
    ----------
    y : array_like
        Dependent variable.
    x : {None, array_like}, optional
        Independent variable. If None, use ``arange(len(y))`` instead.
    alpha : float
        Confidence degree between 0 and 1. Default is 95% confidence.
        Note that `alpha` is symmetric around 0.5, i.e. both 0.1 and 0.9 are
        interpreted as "find the 90% confidence interval".

    Returns
    -------
    medslope : float
        Theil slope.
    medintercept : float
        Intercept of the Theil line, as ``median(y) - medslope*median(x)``.
    lo_slope : float
        Lower bound of the confidence interval on `medslope`.
    up_slope : float
        Upper bound of the confidence interval on `medslope`.

    Notes
    -----
    The implementation of `theilslopes` follows [1]_. The intercept is
    not defined in [1]_, and here it is defined as ``median(y) -
    medslope*median(x)``, which is given in [3]_. Other definitions of
    the intercept exist in the literature. A confidence interval for
    the intercept is not given as this question is not addressed in
    [1]_.

    References
    ----------
    .. [1] P.K. Sen, "Estimates of the regression coefficient based on Kendall's tau",
           J. Am. Stat. Assoc., Vol. 63, pp. 1379-1389, 1968.
    .. [2] H. Theil, "A rank-invariant method of linear and polynomial
           regression analysis I, II and III",  Nederl. Akad. Wetensch., Proc.
           53:, pp. 386-392, pp. 521-525, pp. 1397-1412, 1950.
    .. [3] W.L. Conover, "Practical nonparametric statistics", 2nd ed.,
           John Wiley and Sons, New York, pp. 493.

    Examples
    --------
    >>> from scipy import stats
    >>> import matplotlib.pyplot as plt

    >>> x = np.linspace(-5, 5, num=150)
    >>> y = x + np.random.normal(size=x.size)
    >>> y[11:15] += 10  # add outliers
    >>> y[-5:] -= 7

    Compute the slope, intercept and 90% confidence interval.  For comparison,
    also compute the least-squares fit with `linregress`:

    >>> res = stats.theilslopes(y, x, 0.90)
    >>> lsq_res = stats.linregress(x, y)

    Plot the results. The Theil-Sen regression line is shown in red, with the
    dashed red lines illustrating the confidence interval of the slope (note
    that the dashed red lines are not the confidence interval of the regression
    as the confidence interval of the intercept is not included). The green
    line shows the least-squares fit for comparison.

    >>> fig = plt.figure()
    >>> ax = fig.add_subplot(111)
    >>> ax.plot(x, y, 'b.')
    >>> ax.plot(x, res[1] + res[0] * x, 'r-')
    >>> ax.plot(x, res[1] + res[2] * x, 'r--')
    >>> ax.plot(x, res[1] + res[3] * x, 'r--')
    >>> ax.plot(x, lsq_res[1] + lsq_res[0] * x, 'g-')
    >>> plt.show()

    """
    y = np.asarray(y).flatten()
    if x is None:
        x = np.arange(len(y), dtype=float)
    else:
        x = np.asarray(x, dtype=float).flatten()
        if len(x) != len(y):
            raise ValueError("Incompatible lengths ! (%s<>%s)" % (len(y),len(x)))

    # Compute sorted slopes only when deltax > 0
    deltax = x[:, np.newaxis] - x
    deltay = y[:, np.newaxis] - y
    slopes = deltay[deltax > 0] / deltax[deltax > 0]
    slopes.sort()
    medslope = np.median(slopes)
    medinter = np.median(y) - medslope * np.median(x)
    # Now compute confidence intervals
    if alpha > 0.5:
        alpha = 1. - alpha

    z = distributions.norm.ppf(alpha / 2.)
    # This implements (2.6) from Sen (1968)
    _, nxreps = find_repeats(x)
    _, nyreps = find_repeats(y)
    nt = len(slopes)       # N in Sen (1968)
    ny = len(y)            # n in Sen (1968)
    # Equation 2.6 in Sen (1968):
    sigsq = 1/18. * (ny * (ny-1) * (2*ny+5) -
                     np.sum(k * (k-1) * (2*k + 5) for k in nxreps) -
                     np.sum(k * (k-1) * (2*k + 5) for k in nyreps))
    # Find the confidence interval indices in `slopes`
    sigma = np.sqrt(sigsq)
    Ru = min(int(np.round((nt - z*sigma)/2.)), len(slopes)-1)
    Rl = max(int(np.round((nt + z*sigma)/2.)) - 1, 0)
    delta = slopes[[Rl, Ru]]
    return medslope, medinter, delta[0], delta[1]


#####################################
#####  INFERENTIAL STATISTICS  #####
#####################################

def ttest_1samp(a, popmean, axis=0):
    """
    Calculates the T-test for the mean of ONE group of scores.

    This is a two-sided test for the null hypothesis that the expected value
    (mean) of a sample of independent observations `a` is equal to the given
    population mean, `popmean`.

    Parameters
    ----------
    a : array_like
        sample observation
    popmean : float or array_like
        expected value in null hypothesis, if array_like than it must have the
        same shape as `a` excluding the axis dimension
    axis : int, optional, (default axis=0)
        Axis can equal None (ravel array first), or an integer (the axis
        over which to operate on a).

    Returns
    -------
    t : float or array
        t-statistic
    prob : float or array
        two-tailed p-value

    Examples
    --------
    >>> from scipy import stats

    >>> np.random.seed(7654567)  # fix seed to get the same result
    >>> rvs = stats.norm.rvs(loc=5, scale=10, size=(50,2))

    Test if mean of random sample is equal to true mean, and different mean.
    We reject the null hypothesis in the second case and don't reject it in
    the first case.

    >>> stats.ttest_1samp(rvs,5.0)
    (array([-0.68014479, -0.04323899]), array([ 0.49961383,  0.96568674]))
    >>> stats.ttest_1samp(rvs,0.0)
    (array([ 2.77025808,  4.11038784]), array([ 0.00789095,  0.00014999]))

    Examples using axis and non-scalar dimension for population mean.

    >>> stats.ttest_1samp(rvs,[5.0,0.0])
    (array([-0.68014479,  4.11038784]), array([  4.99613833e-01,   1.49986458e-04]))
    >>> stats.ttest_1samp(rvs.T,[5.0,0.0],axis=1)
    (array([-0.68014479,  4.11038784]), array([  4.99613833e-01,   1.49986458e-04]))
    >>> stats.ttest_1samp(rvs,[[5.0],[0.0]])
    (array([[-0.68014479, -0.04323899],
           [ 2.77025808,  4.11038784]]), array([[  4.99613833e-01,   9.65686743e-01],
           [  7.89094663e-03,   1.49986458e-04]]))

    """
    a, axis = _chk_asarray(a, axis)
    n = a.shape[axis]
    df = n - 1

    d = np.mean(a, axis) - popmean
    v = np.var(a, axis, ddof=1)
    denom = np.sqrt(v / float(n))

    t = np.divide(d, denom)
    t, prob = _ttest_finish(df, t)

    return t, prob


def _ttest_finish(df,t):
    """Common code between all 3 t-test functions."""
    prob = distributions.t.sf(np.abs(t), df) * 2  # use np.abs to get upper tail
    if t.ndim == 0:
        t = t[()]

    return t, prob


def ttest_ind(a, b, axis=0, equal_var=True):
    """
    Calculates the T-test for the means of TWO INDEPENDENT samples of scores.

    This is a two-sided test for the null hypothesis that 2 independent samples
    have identical average (expected) values. This test assumes that the
    populations have identical variances.

    Parameters
    ----------
    a, b : array_like
        The arrays must have the same shape, except in the dimension
        corresponding to `axis` (the first, by default).
    axis : int, optional
        Axis can equal None (ravel array first), or an integer (the axis
        over which to operate on a and b).
    equal_var : bool, optional
        If True (default), perform a standard independent 2 sample test
        that assumes equal population variances [1]_.
        If False, perform Welch's t-test, which does not assume equal
        population variance [2]_.

        .. versionadded:: 0.11.0

    Returns
    -------
    t : float or array
        The calculated t-statistic.
    prob : float or array
        The two-tailed p-value.

    Notes
    -----
    We can use this test, if we observe two independent samples from
    the same or different population, e.g. exam scores of boys and
    girls or of two ethnic groups. The test measures whether the
    average (expected) value differs significantly across samples. If
    we observe a large p-value, for example larger than 0.05 or 0.1,
    then we cannot reject the null hypothesis of identical average scores.
    If the p-value is smaller than the threshold, e.g. 1%, 5% or 10%,
    then we reject the null hypothesis of equal averages.

    References
    ----------
    .. [1] http://en.wikipedia.org/wiki/T-test#Independent_two-sample_t-test

    .. [2] http://en.wikipedia.org/wiki/Welch%27s_t_test

    Examples
    --------
    >>> from scipy import stats
    >>> np.random.seed(12345678)

    Test with sample with identical means:

    >>> rvs1 = stats.norm.rvs(loc=5,scale=10,size=500)
    >>> rvs2 = stats.norm.rvs(loc=5,scale=10,size=500)
    >>> stats.ttest_ind(rvs1,rvs2)
    (0.26833823296239279, 0.78849443369564776)
    >>> stats.ttest_ind(rvs1,rvs2, equal_var = False)
    (0.26833823296239279, 0.78849452749500748)

    `ttest_ind` underestimates p for unequal variances:

    >>> rvs3 = stats.norm.rvs(loc=5, scale=20, size=500)
    >>> stats.ttest_ind(rvs1, rvs3)
    (-0.46580283298287162, 0.64145827413436174)
    >>> stats.ttest_ind(rvs1, rvs3, equal_var = False)
    (-0.46580283298287162, 0.64149646246569292)

    When n1 != n2, the equal variance t-statistic is no longer equal to the
    unequal variance t-statistic:

    >>> rvs4 = stats.norm.rvs(loc=5, scale=20, size=100)
    >>> stats.ttest_ind(rvs1, rvs4)
    (-0.99882539442782481, 0.3182832709103896)
    >>> stats.ttest_ind(rvs1, rvs4, equal_var = False)
    (-0.69712570584654099, 0.48716927725402048)

    T-test with different means, variance, and n:

    >>> rvs5 = stats.norm.rvs(loc=8, scale=20, size=100)
    >>> stats.ttest_ind(rvs1, rvs5)
    (-1.4679669854490653, 0.14263895620529152)
    >>> stats.ttest_ind(rvs1, rvs5, equal_var = False)
    (-0.94365973617132992, 0.34744170334794122)

    """
    a, b, axis = _chk2_asarray(a, b, axis)
    if a.size == 0 or b.size == 0:
        return (np.nan, np.nan)

    v1 = np.var(a, axis, ddof=1)
    v2 = np.var(b, axis, ddof=1)
    n1 = a.shape[axis]
    n2 = b.shape[axis]

    if (equal_var):
        df = n1 + n2 - 2
        svar = ((n1 - 1) * v1 + (n2 - 1) * v2) / float(df)
        denom = np.sqrt(svar * (1.0 / n1 + 1.0 / n2))
    else:
        vn1 = v1 / n1
        vn2 = v2 / n2
        df = ((vn1 + vn2)**2) / ((vn1**2) / (n1 - 1) + (vn2**2) / (n2 - 1))

        # If df is undefined, variances are zero (assumes n1 > 0 & n2 > 0).
        # Hence it doesn't matter what df is as long as it's not NaN.
        df = np.where(np.isnan(df), 1, df)
        denom = np.sqrt(vn1 + vn2)

    d = np.mean(a, axis) - np.mean(b, axis)
    t = np.divide(d, denom)
    t, prob = _ttest_finish(df, t)

    return t, prob


def ttest_rel(a, b, axis=0):
    """
    Calculates the T-test on TWO RELATED samples of scores, a and b.

    This is a two-sided test for the null hypothesis that 2 related or
    repeated samples have identical average (expected) values.

    Parameters
    ----------
    a, b : array_like
        The arrays must have the same shape.
    axis : int, optional, (default axis=0)
        Axis can equal None (ravel array first), or an integer (the axis
        over which to operate on a and b).

    Returns
    -------
    t : float or array
        t-statistic
    prob : float or array
        two-tailed p-value

    Notes
    -----
    Examples for the use are scores of the same set of student in
    different exams, or repeated sampling from the same units. The
    test measures whether the average score differs significantly
    across samples (e.g. exams). If we observe a large p-value, for
    example greater than 0.05 or 0.1 then we cannot reject the null
    hypothesis of identical average scores. If the p-value is smaller
    than the threshold, e.g. 1%, 5% or 10%, then we reject the null
    hypothesis of equal averages. Small p-values are associated with
    large t-statistics.

    References
    ----------
    http://en.wikipedia.org/wiki/T-test#Dependent_t-test

    Examples
    --------
    >>> from scipy import stats
    >>> np.random.seed(12345678) # fix random seed to get same numbers

    >>> rvs1 = stats.norm.rvs(loc=5,scale=10,size=500)
    >>> rvs2 = (stats.norm.rvs(loc=5,scale=10,size=500) +
    ...         stats.norm.rvs(scale=0.2,size=500))
    >>> stats.ttest_rel(rvs1,rvs2)
    (0.24101764965300962, 0.80964043445811562)
    >>> rvs3 = (stats.norm.rvs(loc=8,scale=10,size=500) +
    ...         stats.norm.rvs(scale=0.2,size=500))
    >>> stats.ttest_rel(rvs1,rvs3)
    (-3.9995108708727933, 7.3082402191726459e-005)

    """
    a, b, axis = _chk2_asarray(a, b, axis)
    if a.shape[axis] != b.shape[axis]:
        raise ValueError('unequal length arrays')

    if a.size == 0 or b.size == 0:
        return (np.nan, np.nan)

    n = a.shape[axis]
    df = float(n - 1)

    d = (a - b).astype(np.float64)
    v = np.var(d, axis, ddof=1)
    dm = np.mean(d, axis)
    denom = np.sqrt(v / float(n))

    t = np.divide(dm, denom)
    t, prob = _ttest_finish(df, t)

    return t, prob


def kstest(rvs, cdf, args=(), N=20, alternative='two-sided', mode='approx'):
    """
    Perform the Kolmogorov-Smirnov test for goodness of fit.

    This performs a test of the distribution G(x) of an observed
    random variable against a given distribution F(x). Under the null
    hypothesis the two distributions are identical, G(x)=F(x). The
    alternative hypothesis can be either 'two-sided' (default), 'less'
    or 'greater'. The KS test is only valid for continuous distributions.

    Parameters
    ----------
    rvs : str, array or callable
        If a string, it should be the name of a distribution in `scipy.stats`.
        If an array, it should be a 1-D array of observations of random
        variables.
        If a callable, it should be a function to generate random variables;
        it is required to have a keyword argument `size`.
    cdf : str or callable
        If a string, it should be the name of a distribution in `scipy.stats`.
        If `rvs` is a string then `cdf` can be False or the same as `rvs`.
        If a callable, that callable is used to calculate the cdf.
    args : tuple, sequence, optional
        Distribution parameters, used if `rvs` or `cdf` are strings.
    N : int, optional
        Sample size if `rvs` is string or callable.  Default is 20.
    alternative : {'two-sided', 'less','greater'}, optional
        Defines the alternative hypothesis (see explanation above).
        Default is 'two-sided'.
    mode : 'approx' (default) or 'asymp', optional
        Defines the distribution used for calculating the p-value.

          - 'approx' : use approximation to exact distribution of test statistic
          - 'asymp' : use asymptotic distribution of test statistic

    Returns
    -------
    D : float
        KS test statistic, either D, D+ or D-.
    p-value :  float
        One-tailed or two-tailed p-value.

    Notes
    -----
    In the one-sided test, the alternative is that the empirical
    cumulative distribution function of the random variable is "less"
    or "greater" than the cumulative distribution function F(x) of the
    hypothesis, ``G(x)<=F(x)``, resp. ``G(x)>=F(x)``.

    Examples
    --------
    >>> from scipy import stats

    >>> x = np.linspace(-15, 15, 9)
    >>> stats.kstest(x, 'norm')
    (0.44435602715924361, 0.038850142705171065)

    >>> np.random.seed(987654321) # set random seed to get the same result
    >>> stats.kstest('norm', False, N=100)
    (0.058352892479417884, 0.88531190944151261)

    The above lines are equivalent to:

    >>> np.random.seed(987654321)
    >>> stats.kstest(stats.norm.rvs(size=100), 'norm')
    (0.058352892479417884, 0.88531190944151261)

    *Test against one-sided alternative hypothesis*

    Shift distribution to larger values, so that ``cdf_dgp(x) < norm.cdf(x)``:

    >>> np.random.seed(987654321)
    >>> x = stats.norm.rvs(loc=0.2, size=100)
    >>> stats.kstest(x,'norm', alternative = 'less')
    (0.12464329735846891, 0.040989164077641749)

    Reject equal distribution against alternative hypothesis: less

    >>> stats.kstest(x,'norm', alternative = 'greater')
    (0.0072115233216311081, 0.98531158590396395)

    Don't reject equal distribution against alternative hypothesis: greater

    >>> stats.kstest(x,'norm', mode='asymp')
    (0.12464329735846891, 0.08944488871182088)

    *Testing t distributed random variables against normal distribution*

    With 100 degrees of freedom the t distribution looks close to the normal
    distribution, and the K-S test does not reject the hypothesis that the
    sample came from the normal distribution:

    >>> np.random.seed(987654321)
    >>> stats.kstest(stats.t.rvs(100,size=100),'norm')
    (0.072018929165471257, 0.67630062862479168)

    With 3 degrees of freedom the t distribution looks sufficiently different
    from the normal distribution, that we can reject the hypothesis that the
    sample came from the normal distribution at the 10% level:

    >>> np.random.seed(987654321)
    >>> stats.kstest(stats.t.rvs(3,size=100),'norm')
    (0.131016895759829, 0.058826222555312224)

    """
    if isinstance(rvs, string_types):
        if (not cdf) or (cdf == rvs):
            cdf = getattr(distributions, rvs).cdf
            rvs = getattr(distributions, rvs).rvs
        else:
            raise AttributeError("if rvs is string, cdf has to be the "
                                 "same distribution")

    if isinstance(cdf, string_types):
        cdf = getattr(distributions, cdf).cdf
    if callable(rvs):
        kwds = {'size':N}
        vals = np.sort(rvs(*args,**kwds))
    else:
        vals = np.sort(rvs)
        N = len(vals)
    cdfvals = cdf(vals, *args)

    # to not break compatibility with existing code
    if alternative == 'two_sided':
        alternative = 'two-sided'

    if alternative in ['two-sided', 'greater']:
        Dplus = (np.arange(1.0, N+1)/N - cdfvals).max()
        if alternative == 'greater':
            return Dplus, distributions.ksone.sf(Dplus,N)

    if alternative in ['two-sided', 'less']:
        Dmin = (cdfvals - np.arange(0.0, N)/N).max()
        if alternative == 'less':
            return Dmin, distributions.ksone.sf(Dmin,N)

    if alternative == 'two-sided':
        D = np.max([Dplus,Dmin])
        if mode == 'asymp':
            return D, distributions.kstwobign.sf(D*np.sqrt(N))
        if mode == 'approx':
            pval_two = distributions.kstwobign.sf(D*np.sqrt(N))
            if N > 2666 or pval_two > 0.80 - N*0.3/1000.0:
                return D, distributions.kstwobign.sf(D*np.sqrt(N))
            else:
                return D, distributions.ksone.sf(D,N)*2


# Map from names to lambda_ values used in power_divergence().
_power_div_lambda_names = {
    "pearson": 1,
    "log-likelihood": 0,
    "freeman-tukey": -0.5,
    "mod-log-likelihood": -1,
    "neyman": -2,
    "cressie-read": 2/3,
}


def _count(a, axis=None):
    """
    Count the number of non-masked elements of an array.

    This function behaves like np.ma.count(), but is much faster
    for ndarrays.
    """
    if hasattr(a, 'count'):
        num = a.count(axis=axis)
        if isinstance(num, np.ndarray) and num.ndim == 0:
            # In some cases, the `count` method returns a scalar array (e.g.
            # np.array(3)), but we want a plain integer.
            num = int(num)
    else:
        if axis is None:
            num = a.size
        else:
            num = a.shape[axis]
    return num


def power_divergence(f_obs, f_exp=None, ddof=0, axis=0, lambda_=None):
    """
    Cressie-Read power divergence statistic and goodness of fit test.

    This function tests the null hypothesis that the categorical data
    has the given frequencies, using the Cressie-Read power divergence
    statistic.

    Parameters
    ----------
    f_obs : array_like
        Observed frequencies in each category.
    f_exp : array_like, optional
        Expected frequencies in each category.  By default the categories are
        assumed to be equally likely.
    ddof : int, optional
        "Delta degrees of freedom": adjustment to the degrees of freedom
        for the p-value.  The p-value is computed using a chi-squared
        distribution with ``k - 1 - ddof`` degrees of freedom, where `k`
        is the number of observed frequencies.  The default value of `ddof`
        is 0.
    axis : int or None, optional
        The axis of the broadcast result of `f_obs` and `f_exp` along which to
        apply the test.  If axis is None, all values in `f_obs` are treated
        as a single data set.  Default is 0.
    lambda_ : float or str, optional
        `lambda_` gives the power in the Cressie-Read power divergence
        statistic.  The default is 1.  For convenience, `lambda_` may be
        assigned one of the following strings, in which case the
        corresponding numerical value is used::

            String              Value   Description
            "pearson"             1     Pearson's chi-squared statistic.
                                        In this case, the function is
                                        equivalent to `stats.chisquare`.
            "log-likelihood"      0     Log-likelihood ratio. Also known as
                                        the G-test [3]_.
            "freeman-tukey"      -1/2   Freeman-Tukey statistic.
            "mod-log-likelihood" -1     Modified log-likelihood ratio.
            "neyman"             -2     Neyman's statistic.
            "cressie-read"        2/3   The power recommended in [5]_.

    Returns
    -------
    stat : float or ndarray
        The Cressie-Read power divergence test statistic.  The value is
        a float if `axis` is None or if` `f_obs` and `f_exp` are 1-D.
    p : float or ndarray
        The p-value of the test.  The value is a float if `ddof` and the
        return value `stat` are scalars.

    See Also
    --------
    chisquare

    Notes
    -----
    This test is invalid when the observed or expected frequencies in each
    category are too small.  A typical rule is that all of the observed
    and expected frequencies should be at least 5.

    When `lambda_` is less than zero, the formula for the statistic involves
    dividing by `f_obs`, so a warning or error may be generated if any value
    in `f_obs` is 0.

    Similarly, a warning or error may be generated if any value in `f_exp` is
    zero when `lambda_` >= 0.

    The default degrees of freedom, k-1, are for the case when no parameters
    of the distribution are estimated. If p parameters are estimated by
    efficient maximum likelihood then the correct degrees of freedom are
    k-1-p. If the parameters are estimated in a different way, then the
    dof can be between k-1-p and k-1. However, it is also possible that
    the asymptotic distribution is not a chisquare, in which case this
    test is not appropriate.

    This function handles masked arrays.  If an element of `f_obs` or `f_exp`
    is masked, then data at that position is ignored, and does not count
    towards the size of the data set.

    .. versionadded:: 0.13.0

    References
    ----------
    .. [1] Lowry, Richard.  "Concepts and Applications of Inferential
           Statistics". Chapter 8. http://faculty.vassar.edu/lowry/ch8pt1.html
    .. [2] "Chi-squared test", http://en.wikipedia.org/wiki/Chi-squared_test
    .. [3] "G-test", http://en.wikipedia.org/wiki/G-test
    .. [4] Sokal, R. R. and Rohlf, F. J. "Biometry: the principles and
           practice of statistics in biological research", New York: Freeman
           (1981)
    .. [5] Cressie, N. and Read, T. R. C., "Multinomial Goodness-of-Fit
           Tests", J. Royal Stat. Soc. Series B, Vol. 46, No. 3 (1984),
           pp. 440-464.

    Examples
    --------

    (See `chisquare` for more examples.)

    When just `f_obs` is given, it is assumed that the expected frequencies
    are uniform and given by the mean of the observed frequencies.  Here we
    perform a G-test (i.e. use the log-likelihood ratio statistic):

    >>> power_divergence([16, 18, 16, 14, 12, 12], lambda_='log-likelihood')
    (2.006573162632538, 0.84823476779463769)

    The expected frequencies can be given with the `f_exp` argument:

    >>> power_divergence([16, 18, 16, 14, 12, 12],
    ...                  f_exp=[16, 16, 16, 16, 16, 8],
    ...                  lambda_='log-likelihood')
    (3.5, 0.62338762774958223)

    When `f_obs` is 2-D, by default the test is applied to each column.

    >>> obs = np.array([[16, 18, 16, 14, 12, 12], [32, 24, 16, 28, 20, 24]]).T
    >>> obs.shape
    (6, 2)
    >>> power_divergence(obs, lambda_="log-likelihood")
    (array([ 2.00657316,  6.77634498]), array([ 0.84823477,  0.23781225]))

    By setting ``axis=None``, the test is applied to all data in the array,
    which is equivalent to applying the test to the flattened array.

    >>> power_divergence(obs, axis=None)
    (23.31034482758621, 0.015975692534127565)
    >>> power_divergence(obs.ravel())
    (23.31034482758621, 0.015975692534127565)

    `ddof` is the change to make to the default degrees of freedom.

    >>> power_divergence([16, 18, 16, 14, 12, 12], ddof=1)
    (2.0, 0.73575888234288467)

    The calculation of the p-values is done by broadcasting the
    test statistic with `ddof`.

    >>> power_divergence([16, 18, 16, 14, 12, 12], ddof=[0,1,2])
    (2.0, array([ 0.84914504,  0.73575888,  0.5724067 ]))

    `f_obs` and `f_exp` are also broadcast.  In the following, `f_obs` has
    shape (6,) and `f_exp` has shape (2, 6), so the result of broadcasting
    `f_obs` and `f_exp` has shape (2, 6).  To compute the desired chi-squared
    statistics, we must use ``axis=1``:

    >>> power_divergence([16, 18, 16, 14, 12, 12],
    ...                  f_exp=[[16, 16, 16, 16, 16, 8],
    ...                         [8, 20, 20, 16, 12, 12]],
    ...                  axis=1)
    (array([ 3.5 ,  9.25]), array([ 0.62338763,  0.09949846]))

    """
    # Convert the input argument `lambda_` to a numerical value.
    if isinstance(lambda_, string_types):
        if lambda_ not in _power_div_lambda_names:
            names = repr(list(_power_div_lambda_names.keys()))[1:-1]
            raise ValueError("invalid string for lambda_: {0!r}.  Valid strings "
                "are {1}".format(lambda_, names))
        lambda_ = _power_div_lambda_names[lambda_]
    elif lambda_ is None:
        lambda_ = 1

    f_obs = np.asanyarray(f_obs)

    if f_exp is not None:
        f_exp = np.atleast_1d(np.asanyarray(f_exp))
    else:
        # Compute the equivalent of
        #   f_exp = f_obs.mean(axis=axis, keepdims=True)
        # Older versions of numpy do not have the 'keepdims' argument, so
        # we have to do a little work to achieve the same result.
        # Ignore 'invalid' errors so the edge case of a data set with length 0
        # is handled without spurious warnings.
        with np.errstate(invalid='ignore'):
            f_exp = np.atleast_1d(f_obs.mean(axis=axis))
        if axis is not None:
            reduced_shape = list(f_obs.shape)
            reduced_shape[axis] = 1
            f_exp.shape = reduced_shape

    # `terms` is the array of terms that are summed along `axis` to create
    # the test statistic.  We use some specialized code for a few special
    # cases of lambda_.
    if lambda_ == 1:
        # Pearson's chi-squared statistic
        terms = (f_obs - f_exp)**2 / f_exp
    elif lambda_ == 0:
        # Log-likelihood ratio (i.e. G-test)
        terms = 2.0 * special.xlogy(f_obs, f_obs / f_exp)
    elif lambda_ == -1:
        # Modified log-likelihood ratio
        terms = 2.0 * special.xlogy(f_exp, f_exp / f_obs)
    else:
        # General Cressie-Read power divergence.
        terms = f_obs * ((f_obs / f_exp)**lambda_ - 1)
        terms /= 0.5 * lambda_ * (lambda_ + 1)

    stat = terms.sum(axis=axis)

    num_obs = _count(terms, axis=axis)
    ddof = asarray(ddof)
    p = chisqprob(stat, num_obs - 1 - ddof)

    return stat, p


def chisquare(f_obs, f_exp=None, ddof=0, axis=0):
    """
    Calculates a one-way chi square test.

    The chi square test tests the null hypothesis that the categorical data
    has the given frequencies.

    Parameters
    ----------
    f_obs : array_like
        Observed frequencies in each category.
    f_exp : array_like, optional
        Expected frequencies in each category.  By default the categories are
        assumed to be equally likely.
    ddof : int, optional
        "Delta degrees of freedom": adjustment to the degrees of freedom
        for the p-value.  The p-value is computed using a chi-squared
        distribution with ``k - 1 - ddof`` degrees of freedom, where `k`
        is the number of observed frequencies.  The default value of `ddof`
        is 0.
    axis : int or None, optional
        The axis of the broadcast result of `f_obs` and `f_exp` along which to
        apply the test.  If axis is None, all values in `f_obs` are treated
        as a single data set.  Default is 0.

    Returns
    -------
    chisq : float or ndarray
        The chi-squared test statistic.  The value is a float if `axis` is
        None or `f_obs` and `f_exp` are 1-D.
    p : float or ndarray
        The p-value of the test.  The value is a float if `ddof` and the
        return value `chisq` are scalars.

    See Also
    --------
    power_divergence
    mstats.chisquare

    Notes
    -----
    This test is invalid when the observed or expected frequencies in each
    category are too small.  A typical rule is that all of the observed
    and expected frequencies should be at least 5.

    The default degrees of freedom, k-1, are for the case when no parameters
    of the distribution are estimated. If p parameters are estimated by
    efficient maximum likelihood then the correct degrees of freedom are
    k-1-p. If the parameters are estimated in a different way, then the
    dof can be between k-1-p and k-1. However, it is also possible that
    the asymptotic distribution is not a chisquare, in which case this
    test is not appropriate.

    References
    ----------
    .. [1] Lowry, Richard.  "Concepts and Applications of Inferential
           Statistics". Chapter 8. http://faculty.vassar.edu/lowry/ch8pt1.html
    .. [2] "Chi-squared test", http://en.wikipedia.org/wiki/Chi-squared_test

    Examples
    --------
    When just `f_obs` is given, it is assumed that the expected frequencies
    are uniform and given by the mean of the observed frequencies.

    >>> chisquare([16, 18, 16, 14, 12, 12])
    (2.0, 0.84914503608460956)

    With `f_exp` the expected frequencies can be given.

    >>> chisquare([16, 18, 16, 14, 12, 12], f_exp=[16, 16, 16, 16, 16, 8])
    (3.5, 0.62338762774958223)

    When `f_obs` is 2-D, by default the test is applied to each column.

    >>> obs = np.array([[16, 18, 16, 14, 12, 12], [32, 24, 16, 28, 20, 24]]).T
    >>> obs.shape
    (6, 2)
    >>> chisquare(obs)
    (array([ 2.        ,  6.66666667]), array([ 0.84914504,  0.24663415]))

    By setting ``axis=None``, the test is applied to all data in the array,
    which is equivalent to applying the test to the flattened array.

    >>> chisquare(obs, axis=None)
    (23.31034482758621, 0.015975692534127565)
    >>> chisquare(obs.ravel())
    (23.31034482758621, 0.015975692534127565)

    `ddof` is the change to make to the default degrees of freedom.

    >>> chisquare([16, 18, 16, 14, 12, 12], ddof=1)
    (2.0, 0.73575888234288467)

    The calculation of the p-values is done by broadcasting the
    chi-squared statistic with `ddof`.

    >>> chisquare([16, 18, 16, 14, 12, 12], ddof=[0,1,2])
    (2.0, array([ 0.84914504,  0.73575888,  0.5724067 ]))

    `f_obs` and `f_exp` are also broadcast.  In the following, `f_obs` has
    shape (6,) and `f_exp` has shape (2, 6), so the result of broadcasting
    `f_obs` and `f_exp` has shape (2, 6).  To compute the desired chi-squared
    statistics, we use ``axis=1``:

    >>> chisquare([16, 18, 16, 14, 12, 12],
    ...           f_exp=[[16, 16, 16, 16, 16, 8], [8, 20, 20, 16, 12, 12]],
    ...           axis=1)
    (array([ 3.5 ,  9.25]), array([ 0.62338763,  0.09949846]))

    """
    return power_divergence(f_obs, f_exp=f_exp, ddof=ddof, axis=axis,
                            lambda_="pearson")


def ks_2samp(data1, data2):
    """
    Computes the Kolmogorov-Smirnov statistic on 2 samples.

    This is a two-sided test for the null hypothesis that 2 independent samples
    are drawn from the same continuous distribution.

    Parameters
    ----------
    a, b : sequence of 1-D ndarrays
        two arrays of sample observations assumed to be drawn from a continuous
        distribution, sample sizes can be different

    Returns
    -------
    D : float
        KS statistic
    p-value : float
        two-tailed p-value

    Notes
    -----
    This tests whether 2 samples are drawn from the same distribution. Note
    that, like in the case of the one-sample K-S test, the distribution is
    assumed to be continuous.

    This is the two-sided test, one-sided tests are not implemented.
    The test uses the two-sided asymptotic Kolmogorov-Smirnov distribution.

    If the K-S statistic is small or the p-value is high, then we cannot
    reject the hypothesis that the distributions of the two samples
    are the same.

    Examples
    --------
    >>> from scipy import stats
    >>> np.random.seed(12345678)  #fix random seed to get the same result
    >>> n1 = 200  # size of first sample
    >>> n2 = 300  # size of second sample

    For a different distribution, we can reject the null hypothesis since the
    pvalue is below 1%:

    >>> rvs1 = stats.norm.rvs(size=n1, loc=0., scale=1)
    >>> rvs2 = stats.norm.rvs(size=n2, loc=0.5, scale=1.5)
    >>> stats.ks_2samp(rvs1, rvs2)
    (0.20833333333333337, 4.6674975515806989e-005)

    For a slightly different distribution, we cannot reject the null hypothesis
    at a 10% or lower alpha since the p-value at 0.144 is higher than 10%

    >>> rvs3 = stats.norm.rvs(size=n2, loc=0.01, scale=1.0)
    >>> stats.ks_2samp(rvs1, rvs3)
    (0.10333333333333333, 0.14498781825751686)

    For an identical distribution, we cannot reject the null hypothesis since
    the p-value is high, 41%:

    >>> rvs4 = stats.norm.rvs(size=n2, loc=0.0, scale=1.0)
    >>> stats.ks_2samp(rvs1, rvs4)
    (0.07999999999999996, 0.41126949729859719)

    """
    data1, data2 = map(asarray, (data1, data2))
    n1 = data1.shape[0]
    n2 = data2.shape[0]
    n1 = len(data1)
    n2 = len(data2)
    data1 = np.sort(data1)
    data2 = np.sort(data2)
    data_all = np.concatenate([data1,data2])
    cdf1 = np.searchsorted(data1,data_all,side='right')/(1.0*n1)
    cdf2 = (np.searchsorted(data2,data_all,side='right'))/(1.0*n2)
    d = np.max(np.absolute(cdf1-cdf2))
    # Note: d absolute not signed distance
    en = np.sqrt(n1*n2/float(n1+n2))
    try:
        prob = distributions.kstwobign.sf((en + 0.12 + 0.11 / en) * d)
    except:
        prob = 1.0
    return d, prob


def mannwhitneyu(x, y, use_continuity=True):
    """
    Computes the Mann-Whitney rank test on samples x and y.

    Parameters
    ----------
    x, y : array_like
        Array of samples, should be one-dimensional.
    use_continuity : bool, optional
            Whether a continuity correction (1/2.) should be taken into
            account. Default is True.

    Returns
    -------
    u : float
        The Mann-Whitney statistics.
    prob : float
        One-sided p-value assuming a asymptotic normal distribution.

    Notes
    -----
    Use only when the number of observation in each sample is > 20 and
    you have 2 independent samples of ranks. Mann-Whitney U is
    significant if the u-obtained is LESS THAN or equal to the critical
    value of U.

    This test corrects for ties and by default uses a continuity correction.
    The reported p-value is for a one-sided hypothesis, to get the two-sided
    p-value multiply the returned p-value by 2.

    """
    x = asarray(x)
    y = asarray(y)
    n1 = len(x)
    n2 = len(y)
    ranked = rankdata(np.concatenate((x,y)))
    rankx = ranked[0:n1]       # get the x-ranks
    u1 = n1*n2 + (n1*(n1+1))/2.0 - np.sum(rankx,axis=0)  # calc U for x
    u2 = n1*n2 - u1                            # remainder is U for y
    bigu = max(u1,u2)
    smallu = min(u1,u2)
    T = tiecorrect(ranked)
    if T == 0:
        raise ValueError('All numbers are identical in amannwhitneyu')
    sd = np.sqrt(T*n1*n2*(n1+n2+1)/12.0)

    if use_continuity:
        # normal approximation for prob calc with continuity correction
        z = abs((bigu-0.5-n1*n2/2.0) / sd)
    else:
        z = abs((bigu-n1*n2/2.0) / sd)  # normal approximation for prob calc
    return smallu, distributions.norm.sf(z)  # (1.0 - zprob(z))


def ranksums(x, y):
    """
    Compute the Wilcoxon rank-sum statistic for two samples.

    The Wilcoxon rank-sum test tests the null hypothesis that two sets
    of measurements are drawn from the same distribution.  The alternative
    hypothesis is that values in one sample are more likely to be
    larger than the values in the other sample.

    This test should be used to compare two samples from continuous
    distributions.  It does not handle ties between measurements
    in x and y.  For tie-handling and an optional continuity correction
    see `scipy.stats.mannwhitneyu`.

    Parameters
    ----------
    x,y : array_like
        The data from the two samples

    Returns
    -------
    z-statistic : float
        The test statistic under the large-sample approximation that the
        rank sum statistic is normally distributed
    p-value : float
        The two-sided p-value of the test

    References
    ----------
    .. [1] http://en.wikipedia.org/wiki/Wilcoxon_rank-sum_test

    """
    x,y = map(np.asarray, (x, y))
    n1 = len(x)
    n2 = len(y)
    alldata = np.concatenate((x,y))
    ranked = rankdata(alldata)
    x = ranked[:n1]
    y = ranked[n1:]
    s = np.sum(x,axis=0)
    expected = n1*(n1+n2+1) / 2.0
    z = (s - expected) / np.sqrt(n1*n2*(n1+n2+1)/12.0)
    prob = 2 * distributions.norm.sf(abs(z))
    return z, prob


def kruskal(*args):
    """
    Compute the Kruskal-Wallis H-test for independent samples

    The Kruskal-Wallis H-test tests the null hypothesis that the population
    median of all of the groups are equal.  It is a non-parametric version of
    ANOVA.  The test works on 2 or more independent samples, which may have
    different sizes.  Note that rejecting the null hypothesis does not
    indicate which of the groups differs.  Post-hoc comparisons between
    groups are required to determine which groups are different.

    Parameters
    ----------
    sample1, sample2, ... : array_like
       Two or more arrays with the sample measurements can be given as
       arguments.

    Returns
    -------
    H-statistic : float
       The Kruskal-Wallis H statistic, corrected for ties
    p-value : float
       The p-value for the test using the assumption that H has a chi
       square distribution

    Notes
    -----
    Due to the assumption that H has a chi square distribution, the number
    of samples in each group must not be too small.  A typical rule is
    that each sample must have at least 5 measurements.

    References
    ----------
    .. [1] http://en.wikipedia.org/wiki/Kruskal-Wallis_one-way_analysis_of_variance

    """
    args = list(map(np.asarray, args))  # convert to a numpy array
    na = len(args)     # Kruskal-Wallis on 'na' groups, each in it's own array
    if na < 2:
        raise ValueError("Need at least two groups in stats.kruskal()")
    n = np.asarray(list(map(len, args)))

    alldata = np.concatenate(args)

    ranked = rankdata(alldata)  # Rank the data
    T = tiecorrect(ranked)      # Correct for ties
    if T == 0:
        raise ValueError('All numbers are identical in kruskal')

    # Compute sum^2/n for each group and sum
    j = np.insert(np.cumsum(n), 0, 0)
    ssbn = 0
    for i in range(na):
        ssbn += square_of_sums(ranked[j[i]:j[i+1]]) / float(n[i])

    totaln = np.sum(n)
    h = 12.0 / (totaln * (totaln + 1)) * ssbn - 3 * (totaln + 1)
    df = na - 1
    h = h / float(T)
    return h, chisqprob(h, df)


def friedmanchisquare(*args):
    """
    Computes the Friedman test for repeated measurements

    The Friedman test tests the null hypothesis that repeated measurements of
    the same individuals have the same distribution.  It is often used
    to test for consistency among measurements obtained in different ways.
    For example, if two measurement techniques are used on the same set of
    individuals, the Friedman test can be used to determine if the two
    measurement techniques are consistent.

    Parameters
    ----------
    measurements1, measurements2, measurements3... : array_like
        Arrays of measurements.  All of the arrays must have the same number
        of elements.  At least 3 sets of measurements must be given.

    Returns
    -------
    friedman chi-square statistic : float
        the test statistic, correcting for ties
    p-value : float
        the associated p-value assuming that the test statistic has a chi
        squared distribution

    Notes
    -----
    Due to the assumption that the test statistic has a chi squared
    distribution, the p-value is only reliable for n > 10 and more than
    6 repeated measurements.

    References
    ----------
    .. [1] http://en.wikipedia.org/wiki/Friedman_test

    """
    k = len(args)
    if k < 3:
        raise ValueError('\nLess than 3 levels.  Friedman test not appropriate.\n')

    n = len(args[0])
    for i in range(1, k):
        if len(args[i]) != n:
            raise ValueError('Unequal N in friedmanchisquare.  Aborting.')

    # Rank data
    data = np.vstack(args).T
    data = data.astype(float)
    for i in range(len(data)):
        data[i] = rankdata(data[i])

    # Handle ties
    ties = 0
    for i in range(len(data)):
        replist, repnum = find_repeats(array(data[i]))
        for t in repnum:
            ties += t*(t*t-1)
    c = 1 - ties / float(k*(k*k-1)*n)

    ssbn = pysum(pysum(data)**2)
    chisq = (12.0 / (k*n*(k+1)) * ssbn - 3*n*(k+1)) / c
    return chisq, chisqprob(chisq,k-1)


#####################################
####  PROBABILITY CALCULATIONS  ####
#####################################

zprob = np.deprecate(message='zprob is deprecated in scipy 0.14, '
        'use norm.cdf or special.ndtr instead\n',
        old_name='zprob')(special.ndtr)


def chisqprob(chisq, df):
    """
    Probability value (1-tail) for the Chi^2 probability distribution.

    Broadcasting rules apply.

    Parameters
    ----------
    chisq : array_like or float > 0

    df : array_like or float, probably int >= 1

    Returns
    -------
    chisqprob : ndarray
        The area from `chisq` to infinity under the Chi^2 probability
        distribution with degrees of freedom `df`.

    """
    return special.chdtrc(df,chisq)

ksprob = np.deprecate(message='ksprob is deprecated in scipy 0.14, '
        'use stats.kstwobign.sf or special.kolmogorov instead\n',
        old_name='ksprob')(special.kolmogorov)

fprob = np.deprecate(message='fprob is deprecated in scipy 0.14, '
        'use stats.f.sf or special.fdtrc instead\n',
        old_name='fprob')(special.fdtrc)


def betai(a, b, x):
    """
    Returns the incomplete beta function.

    I_x(a,b) = 1/B(a,b)*(Integral(0,x) of t^(a-1)(1-t)^(b-1) dt)

    where a,b>0 and B(a,b) = G(a)*G(b)/(G(a+b)) where G(a) is the gamma
    function of a.

    The standard broadcasting rules apply to a, b, and x.

    Parameters
    ----------
    a : array_like or float > 0

    b : array_like or float > 0

    x : array_like or float
        x will be clipped to be no greater than 1.0 .

    Returns
    -------
    betai : ndarray
        Incomplete beta function.

    """
    x = np.asarray(x)
    x = np.where(x < 1.0, x, 1.0)  # if x > 1 then return 1.0
    return special.betainc(a, b, x)


#####################################
#######  ANOVA CALCULATIONS  #######
#####################################

def f_value_wilks_lambda(ER, EF, dfnum, dfden, a, b):
    """Calculation of Wilks lambda F-statistic for multivarite data, per
    Maxwell & Delaney p.657.
    """
    if isinstance(ER, (int, float)):
        ER = array([[ER]])
    if isinstance(EF, (int, float)):
        EF = array([[EF]])
    lmbda = linalg.det(EF) / linalg.det(ER)
    if (a-1)**2 + (b-1)**2 == 5:
        q = 1
    else:
        q = np.sqrt(((a-1)**2*(b-1)**2 - 2) / ((a-1)**2 + (b-1)**2 - 5))
    n_um = (1 - lmbda**(1.0/q))*(a-1)*(b-1)
    d_en = lmbda**(1.0/q) / (n_um*q - 0.5*(a-1)*(b-1) + 1)
    return n_um / d_en


def f_value(ER, EF, dfR, dfF):
    """
    Returns an F-statistic for a restricted vs. unrestricted model.

    Parameters
    ----------
    ER : float
         `ER` is the sum of squared residuals for the restricted model
          or null hypothesis

    EF : float
         `EF` is the sum of squared residuals for the unrestricted model
          or alternate hypothesis

    dfR : int
          `dfR` is the degrees of freedom in the restricted model

    dfF : int
          `dfF` is the degrees of freedom in the unrestricted model

    Returns
    -------
    F-statistic : float

    """
    return ((ER-EF)/float(dfR-dfF) / (EF/float(dfF)))


def f_value_multivariate(ER, EF, dfnum, dfden):
    """
    Returns a multivariate F-statistic.

    Parameters
    ----------
    ER : ndarray
        Error associated with the null hypothesis (the Restricted model).
        From a multivariate F calculation.
    EF : ndarray
        Error associated with the alternate hypothesis (the Full model)
        From a multivariate F calculation.
    dfnum : int
        Degrees of freedom the Restricted model.
    dfden : int
        Degrees of freedom associated with the Restricted model.

    Returns
    -------
    fstat : float
        The computed F-statistic.

    """
    if isinstance(ER, (int, float)):
        ER = array([[ER]])
    if isinstance(EF, (int, float)):
        EF = array([[EF]])
    n_um = (linalg.det(ER) - linalg.det(EF)) / float(dfnum)
    d_en = linalg.det(EF) / float(dfden)
    return n_um / d_en


#####################################
#######  SUPPORT FUNCTIONS  ########
#####################################

def ss(a, axis=0):
    """
    Squares each element of the input array, and returns the sum(s) of that.

    Parameters
    ----------
    a : array_like
        Input array.
    axis : int or None, optional
        The axis along which to calculate. If None, use whole array.
        Default is 0, i.e. along the first axis.

    Returns
    -------
    ss : ndarray
        The sum along the given axis for (a**2).

    See also
    --------
    square_of_sums : The square(s) of the sum(s) (the opposite of `ss`).

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.array([1., 2., 5.])
    >>> stats.ss(a)
    30.0

    And calculating along an axis:

    >>> b = np.array([[1., 2., 5.], [2., 5., 6.]])
    >>> stats.ss(b, axis=1)
    array([ 30., 65.])

    """
    a, axis = _chk_asarray(a, axis)
    return np.sum(a*a, axis)


def square_of_sums(a, axis=0):
    """
    Sums elements of the input array, and returns the square(s) of that sum.

    Parameters
    ----------
    a : array_like
        Input array.
    axis : int or None, optional
        If axis is None, ravel `a` first. If `axis` is an integer, this will
        be the axis over which to operate. Defaults to 0.

    Returns
    -------
    square_of_sums : float or ndarray
        The square of the sum over `axis`.

    See also
    --------
    ss : The sum of squares (the opposite of `square_of_sums`).

    Examples
    --------
    >>> from scipy import stats
    >>> a = np.arange(20).reshape(5,4)
    >>> stats.square_of_sums(a)
    array([ 1600.,  2025.,  2500.,  3025.])
    >>> stats.square_of_sums(a, axis=None)
    36100.0

    """
    a, axis = _chk_asarray(a, axis)
    s = np.sum(a,axis)
    if not np.isscalar(s):
        return s.astype(float)*s
    else:
        return float(s)*s


def fastsort(a):
    """
    Sort an array and provide the argsort.

    Parameters
    ----------
    a : array_like
        Input array.

    Returns
    -------
    fastsort : ndarray of type int
        sorted indices into the original array

    """
    # TODO: the wording in the docstring is nonsense.
    it = np.argsort(a)
    as_ = a[it]
    return as_, it