naginterfaces.library.tsa.cp_​binary

naginterfaces.library.tsa.cp_binary(ctype, y, beta=None, minss=2, param=None, mdepth=0)

cp_binary detects change points in a univariate time series, that is, the time points at which some feature of the data, for example the mean, changes. Change points are detected using binary segmentation using one of a provided set of cost functions.

For full information please refer to the NAG Library document for g13nd

https://www.nag.com/numeric/nl/nagdoc_29.3/flhtml/g13/g13ndf.html

Parameters

ctypeint

A flag indicating the assumed distribution of the data and the type of change point being looked for.

$ctype=1$

Data from a Normal distribution, looking for changes in the mean, $\mu$.

$ctype=2$

Data from a Normal distribution, looking for changes in the standard deviation $\sigma$.

$ctype=3$

Data from a Normal distribution, looking for changes in the mean, $\mu$ and standard deviation $\sigma$.

$ctype=4$

Data from a Gamma distribution, looking for changes in the scale parameter $b$.

$ctype=5$

Data from an exponential distribution, looking for changes in $\lambda$.

$ctype=6$

Data from a Poisson distribution, looking for changes in $\lambda$.

yfloat, array-like, shape $\left(n\right)$

$y$, the time series.

If $ctype=6$, that is the data is assumed to come from a Poisson distribution, $floor\left(y+0.5\right)$ is used in all calculations.

betaNone or float, optional

Note: if this argument is None then a default value will be used, determined as follows: if $ctype=3$: $2\times \log n$; otherwise: $\log n$.

$\beta$, the penalty term.

There are a number of standard ways of setting $\beta$, including:

SIC or BIC

$\beta =p\times \log \left(n\right)$

AIC

$\beta =2p$

Hannan-Quinn

$\beta =2p\times \log \left(\log \left(n\right)\right)$

where $p$ is the number of parameters being treated as estimated in each segment.

This is usually set to $2$ when $ctype=3$ and $1$ otherwise.

If no penalty is required then set $\beta =0$.

Generally, the smaller the value of $\beta$ the larger the number of suggested change points.

minssint, optional

The minimum distance between two change points, that is ${\tau }_i-{\tau }_{i-1}\ge minss$.

paramNone or float, array-like, shape $\left(1\right)$, optional

$\varphi$, values for the parameters that will be treated as fixed. If $ctype=4$ then $param$ must be supplied.

If supplied, then when

$ctype=1$

$param\left[0\right]=\sigma$, the standard deviation of the normal distribution. If not supplied then $\sigma$ is estimated from the full input data,

$ctype=2$

$param\left[0\right]=\mu$, the mean of the normal distribution. If not supplied then $\mu$ is estimated from the full input data,

$ctype=4$

$param\left[0\right]$ must hold the shape, $a$, for the gamma distribution,

otherwise

$param$ is not referenced.

mdepthint, optional

$K$, the maximum depth for the iterative process, which in turn puts an upper limit on the number of change points with $m\le 2^K$.

If $K\le 0$ then no limit is put on the depth of the iterative process and no upper limit is put on the number of change points, other than that inherent in the length of the series and the value of $minss$.

Returns

ntauint

$m$, the number of change points detected.

tauint, ndarray, shape $\left(ntau\right)$

The first $m$ elements of $tau$ hold the location of the change points. The $i$th segment is defined by $y_{({\tau }_{i-1}+1)}$ to $y_{{\tau }_i}$, where ${\tau }_0=0$ and ${\tau }_i=tau[i-1],1\le i\le m$.

sparamfloat, ndarray, shape $(:)$ or $(:,:)$

The estimated values of the distribution parameters in each segment

$ctype=1$, $2$ or $3$

$sparam[0,i-1]={\mu }_i$ and $sparam[1,i-1]={\sigma }_i$ for $i=1,2,\dots ,m$, where ${\mu }_i$ and ${\sigma }_i$ is the mean and standard deviation, respectively, of the values of $y$ in the $i$th segment.

It should be noted that ${\sigma }_i={\sigma }_j$ when $ctype=1$ and ${\mu }_i={\mu }_j$ when $ctype=2$, for all $i$ and $j$.

$ctype=4$

$sparam[0,i-1]=a_i$ and $sparam[1,i-1]=b_i$ for $i=1,2,\dots ,m$, where $a_i$ and $b_i$ are the shape and scale parameters, respectively, for the values of $y$ in the $i$th segment. It should be noted that $a_i=param\left[0\right]$ for all $i$.

$ctype=5$ or $6$

$sparam[i-1]={\lambda }_i$ for $i=1,2,\dots ,m$, where ${\lambda }_i$ is the mean of the values of $y$ in the $i$th segment.

Raises

NagValueError

(errno $11$)

On entry, $ctype=⟨value⟩$.

Constraint: $ctype=1$, $2$, $3$, $4$, $5$ or $6$.

(errno $21$)

On entry, $n=⟨value⟩$.

Constraint: $n\ge 2$.

(errno $31$)

On entry, $ctype=⟨value⟩$ and $y[⟨value⟩]=⟨value⟩$.

Constraint: if $ctype=4$, $5$ or $6$ then $y[\text{i}-1]\ge 0.0$, for $\text{i}=1,2,\dots ,n$.

(errno $32$)

On entry, $y[⟨value⟩]=⟨value⟩$, is too large.

(errno $51$)

On entry, $minss=⟨value⟩$.

Constraint: $minss\ge 2$.

(errno $71$)

On entry, $ctype=⟨value⟩$ and $param\left[0\right]=⟨value⟩$.

Constraint: if $ctype=1$ or $4$ and $param$ has been supplied, then $param\left[0\right]>0.0$.

Warns

NagAlgorithmicWarning

(errno $200$)

To avoid overflow some truncation occurred when calculating the cost function, $C$. All output is returned as normal.

(errno $201$)

To avoid overflow some truncation occurred when calculating the parameter estimates returned in $sparam$. All output is returned as normal.

Notes

Let $y_{1:n}=\{y_j:j=1,2,\dots ,n\}$ denote a series of data and $\tau =\{{\tau }_i:i=1,2,\dots ,m\}$ denote a set of $m$ ordered (strictly monotonic increasing) indices known as change points, with $1\le {\tau }_i\le n$ and ${\tau }_m=n$. For ease of notation we also define ${\tau }_0=0$. The $m$ change points, $\tau$, split the data into $m$ segments, with the $i$th segment being of length $n_i$ and containing $y_{{\tau }_{i-1}+1:{\tau }_i}$.

Given a cost function, $C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)$, cp_binary gives an approximate solution to

$${\text{minimize}}_{m,\tau }\sum _{i=1}^m(C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)+\beta )$$

where $\beta$ is a penalty term used to control the number of change points. The solution is obtained in an iterative manner as follows:

1. Set $u=1$, $w=n$ and $k=0$

2. Set $k=k+1$. If $k>K$, where $K$ is a user-supplied control parameter, then terminate the process for this segment.

3. Find $v$ that minimizes

   $$C\left(y_{u:v}\right)+C\left(y_{v+1:w}\right)$$

4. Test

   $$C\left(y_{u:v}\right)+C\left(y_{v+1:w}\right)+\beta <C\left(y_{u:w}\right)$$

5. If inequality [equation] is false then the process is terminated for this segment.

6. If inequality [equation] is true, then $v$ is added to the set of change points, and the segment is split into two subsegments, $y_{u:v}$ and $y_{v+1:w}$. The whole process is repeated from step 2 independently on each subsegment, with the relevant changes to the definition of $u$ and $w$ (i.e., $w$ is set to $v$ when processing the left-hand subsegment and $u$ is set to $v+1$ when processing the right-hand subsegment.

The change points are ordered to give $\tau$.

cp_binary supplies four families of cost function. Each cost function assumes that the series, $y$, comes from some distribution, $D\left(\Theta \right)$. The parameter space, $\Theta =\{\theta ,\varphi \}$ is subdivided into $\theta$ containing those parameters allowed to differ in each segment and $\varphi$ those parameters treated as constant across all segments. All four cost functions can then be described in terms of the likelihood function, $L$ and are given by:

$$C\left(y_{({\tau }_{i-1}+1):{\tau }_i}\right)=-2\log \left(L({\hat{\theta }}_i,\varphi |y_{({\tau }_{i-1}+1):{\tau }_i})\right)$$

where the ${\hat{\theta }}_i$ is the maximum likelihood estimate of $\theta$ within the $i$th segment. Four distributions are available; Normal, Gamma, Exponential and Poisson distributions. Letting

$$S_i=\sum _{j={\tau }_{i-1}}^{{\tau }_i}{y}_j$$

the log-likelihoods and cost functions for the four distributions, and the available subdivisions of the parameter space are:

Normal distribution: $\Theta =\{\mu ,{\sigma }^2\}$

$$-2\log \left(L\right)=\sum _{i=1}^m\sum _{j={\tau }_{i-1}}^{{\tau }_i}\log \left(2\pi \right)+\log \left({\sigma }_i^2\right)+\frac{{(y_j-{\mu }_i)}^2}{{\sigma }_i^2}$$

Mean changes: $\theta =\left\{\mu \right\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=\sum _{j={\tau }_{i-1}}^{{\tau }_i}\frac{{(y_j-n_i^{-1}{S}_i)}^2}{{\sigma }^2}$$

Variance changes: $\theta =\left\{{\sigma }^2\right\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=n_i(\log \left(\sum _{j={\tau }_{i-1}}^{{\tau }_i}{(y_j-\mu )}^2\right)-\log \left(n_i\right))$$

Both mean and variance change: $\theta =\{\mu ,{\sigma }^2\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=n_i(\log \left(\sum _{j={\tau }_{i-1}}^{{\tau }_i}{(y_j-n_i^{-1}{S}_i)}^2\right)-\log \left(n_i\right))$$

Gamma distribution: $\Theta =\{a,b\}$

$$-2\log \left(L\right)=2\times \sum _{i=1}^m\sum _{j={\tau }_{i-1}}^{{\tau }_i}\log \left(\Gamma \left(a_i\right)\right)+a_i\log \left(b_i\right)+(1-a_i)\log \left(y_j\right)+\frac{y_j}{b_i}$$

Scale changes: $\theta =\left\{b\right\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=2a{n}_i(\log \left(S_i\right)-\log \left(a{n}_i\right))$$

Exponential Distribution: $\Theta =\left\{\lambda \right\}$

$$-2\log \left(L\right)=2\times \sum _{i=1}^m\sum _{j={\tau }_{i-1}}^{{\tau }_i}\log \left({\lambda }_i\right)+\frac{y_j}{{\lambda }_i}$$

Mean changes: $\theta =\left\{\lambda \right\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=2n_i(\log \left(S_i\right)-\log \left(n_i\right))$$

Poisson distribution: $\Theta =\left\{\lambda \right\}$

$$-2\log \left(L\right)=2\times \sum _{i=1}^m\sum _{j={\tau }_{i-1}}^{{\tau }_i}{\lambda }_i-floor\left(y_j+0.5\right)\log \left({\lambda }_i\right)+\log \left(\Gamma (floor\left(y_j+0.5\right)+1)\right)$$

Mean changes: $\theta =\left\{\lambda \right\}$

$$C\left(y_{{\tau }_{i-1}+1:{\tau }_i}\right)=2S_i(\log \left(n_i\right)-\log \left(S_i\right))$$

when calculating $S_i$ for the Poisson distribution, the sum is calculated for $floor\left(y_i+0.5\right)$ rather than $y_i$.

References

Chen, J and Gupta, A K, 2010, Parametric Statistical Change Point Analysis With Applications to Genetics, Medicine and Finance (Second Edition), Birkhäuser

West, D H D, 1979, Updating mean and variance estimates: An improved method, Comm. ACM (22), 532–555