The Poisson distribution for a random variable *Y* has the following probability mass function for a given value *Y* = *y*:

\(\begin{equation*}

\mbox{P}(Y=y|\lambda)=\dfrac{e^{-\lambda}\lambda^{y}}{y!},

\end{equation*}\)

for \(y=0,1,2,\ldots\). Notice that the Poisson distribution is characterized by the single parameter \(\lambda\), which is the mean rate of occurrence for the event being measured. For the Poisson distribution, it is assumed that large counts (concerning the value of \(\lambda\)) are rare.

In **Poisson regression**, the dependent variable (*Y*) is an observed count that follows the Poisson distribution. The rate \(\lambda\) is determined by a set of \(p-1\) predictors \(\textbf{X}=(X_{1},\ldots,X_{p-1})\). The expression relating to these quantities is

\(\begin{equation*}

\lambda=\exp\{\textbf{X}\beta\}.

\end{equation*}\)

Thus, the fundamental Poisson regression model for observation *i* is given by

\(\begin{equation*}

\mbox{P}(Y_{i}=y_{i}|\textbf{X}_{i},\beta)=\dfrac{e^{-\exp\{\textbf{X}_{i}\beta\}}\exp\{\textbf{X}_{i}\beta\}^{y_{i}}}{y_{i}!}.

\end{equation*}\)

That is, for a given set of predictors, the categorical outcome follows a Poisson distribution with rate $\exp\{\textbf{X}\beta\}$. For a sample of size *n*, the likelihood for a Poisson regression is given by:

\(\begin{equation*}

L(\beta;\textbf{y},\textbf{X})=\prod_{i=1}^{n}\dfrac{e^{-\exp\{\textbf{X}_{i}\beta\}}\exp\{\textbf{X}_{i}\beta\}^{y_{i}}}{y_{i}!}.

\end{equation*}\)

This yields the log-likelihood:

\(\begin{equation*}

\ell(\beta)=\sum_{i=1}^{n}y_{i}\textbf{X}_{i}\beta-\sum_{i=1}^{n}\exp\{\textbf{X}_{i}\beta\}-\sum_{i=1}^{n}\log(y_{i}!).

\end{equation*}\)

Maximizing the likelihood (or log-likelihood) has no closed-form solution, so a technique like iteratively reweighted least squares is used to find an estimate of the regression coefficients, \(\hat{\beta}\). Once this value of \(\hat{\beta}\) has been obtained, we may proceed to define various goodness-of-fit measures and calculated residuals. The residuals we present serve the same purpose as in linear regression. When plotted versus the response, they will help identify suspect data points.

To illustrate consider this example (Poisson Simulated data), which consists of a simulated data set of size *n* = 30 such that the response (*Y*) follows a Poisson distribution with the rate $\lambda=\exp\{0.50+0.07X\}$. A plot of the response versus the predictor is given below.

The following gives the analysis of the Poisson regression data in Minitab:

- Select Stat > Regression > Poisson Regression > Fit Poisson Model.
- Select "y" for the Response.
- Select "x" as a Continuous predictor.
- Click Results and change "Display of results" to "Expanded tables."

This results in the following output:

## Coefficients

Term | Coef | SE Coef | 95% CI | Z-Value | P-Value | VIF |
---|---|---|---|---|---|---|

Constant | 0.308 | 0.289 | (-0.259, 0.875) | 1.06 | 0.287 | |

x | 0.0764 | 0.0173 | (0.0424, 0.1103) | 4.41 | 0.000 | 1.00 |

## Regression Equation

y = exp(Y')

Y' = 0.308 + 0.0764 x

As you can see, the Wald test *p*-value for *x* of 0.000 indicates that the predictor is highly significant.

### Deviance Test

Changes in the deviance can be used to test the null hypothesis that any subset of the \(\beta\)'s is equal to 0. The deviance, \(D(\hat{\beta})\), is \(-2\) times the difference between the log-likelihood evaluated at the maximum likelihood estimate and the log-likelihood for a "saturated model" (a theoretical model with a separate parameter for each observation and thus a perfect fit). Suppose we test that *r* < *p* of the $\beta$'s are equal to 0. Then the deviance test statistic is given by:

\(\begin{equation*}

G^2=D(\hat{\beta}^{(0)})-D(\hat{\beta}),

\end{equation*}\)

where \(D(\hat{\beta})\) is the deviance of the fitted (full) model and \(D(\hat{\beta}^{(0)})\) is the deviance of the model specified by the null hypothesis evaluated at the maximum likelihood estimate of that reduced model. This test statistic has a \(\chi^{2}\) distribution with \(p-r\) degrees of freedom. This test procedure is analogous to the general linear F test procedure for multiple linear regression.

To illustrate, the relevant Minitab output from the simulated example is:

## Deviance Table

Source | DF | Seq Dev | Contribution | Adj Dev | Adj Mean | Chi-Square | P-Value |
---|---|---|---|---|---|---|---|

Regression | 1 | 20.47 | 42.37% | 20.47 | 20.4677 | 20.47 | 0.000 |

x | 1 | 20.47 | 42.37% | 20.47 | 20.4677 | 20.47 | 0.000 |

Error | 28 | 27.84 | 57.63% | 27.84 | 0.9944 | ||

Total | 29 | 48.31 | 100.00% |

Since there is only a single predictor for this example, this table simply provides information on the deviance test for *x* (*p*-value of 0.000), which matches the earlier Wald test result (*p*-value of 0.000). (Note that the Wald test and deviance test will *not* in general give identical results.) The Deviance Table includes the following:

- The null model in this case has no predictors, so the fitted values are simply the sample mean, \(4.233\). The deviance for the null model is \(D(\hat{\beta}^{(0)})=48.31\), which is shown in the "Total" row in the Deviance Table.
- The deviance for the fitted model is \(D(\hat{\beta})=27.84\), which is shown in the "Error" row in the Deviance Table.
- The deviance test statistic is therefore \(G^2=48.31-27.84=20.47\).
- The
*p*-value comes from a $\chi^{2}$ distribution with \(2-1=1\) degrees of freedom.

### Goodness-of-Fit

The overall performance of the fitted model can be measured by two different chi-square tests. There is the **Pearson statistic**

\(\begin{equation*}

X^2=\sum_{i=1}^{n}\dfrac{(y_{i}-\exp\{\textbf{X}_{i}\hat{\beta}\})^{2}}{\exp\{\textbf{X}_{i}\hat{\beta}\}}

\end{equation*}\)

and the **deviance statistic**

\(\begin{equation*}

D=2\sum_{i=1}^{n}\biggl(y_{i}\log\biggl(\dfrac{y_{i}}{\exp\{\textbf{X}_{i}\hat{\beta}\}}\biggr)-(y_{i}-\exp\{\textbf{X}_{i}\hat{\beta}\})\biggr).

\end{equation*}\)

Both of these statistics are approximately chi-square distributed with *n* - *p* degrees of freedom. When a test is rejected, there is a statistically significant lack of fit. Otherwise, there is no evidence of a lack of fit.

To illustrate, the relevant Minitab output from the simulated example is:

## Goodness-of-Fit

Test | DF | Estimate | Mean | Chi-Square | P-Value |
---|---|---|---|---|---|

Deviance | 28 | 27.84209 | 0.099436 | 27.84 | 0.473 |

Pearson | 28 | 26.09324 | 0.93190 | 26.09 | 0.568 |

The high *p*-values indicate no evidence of a lack of fit.

**Overdispersion** means that the actual covariance matrix for the observed data exceeds that for the specified model for \(Y|\textbf{X}\). For a Poisson distribution, the mean and the variance are equal. In practice, the data rarely reflects this fact and we have overdispersion in the Poisson regression model if (as is often the case) the variance is greater than the mean. In addition to testing goodness-of-fit, the Pearson statistic can also be used as a test of overdispersion. Note that overdispersion can also be measured in the logistic regression models that were discussed earlier.

### Pseudo \(R^{2}\)

The value of \(R^{2}\) used in linear regression also does not extend to Poisson regression. One commonly used measure is the **pseudo \(R^{2}\)**, defined as

\(\begin{equation*}

R^{2}=\dfrac{\ell(\hat{\beta_{0}})-\ell(\hat{\beta})}{\ell(\hat{\beta_{0}})}=1-\dfrac{D(\hat{\beta})}{D(\hat{\beta_{0}})},

\end{equation*}\)

where \(\ell(\hat{\beta_{0}})\) is the log-likelihood of the model when only the intercept is included. The pseudo \(R^{2}\) goes from 0 to 1 with 1 being a perfect fit.

To illustrate, the relevant Minitab output from the simulated example is:

## Model Summary

Deviance R-Sq |
Deviance R-Sq(adj) |
AIC |
---|---|---|

42.37% | 40.30% | 124.50 |

Recall from above that \(D(\hat{\beta})=27.84\) and \(D(\hat{\beta}^{(0)})=48.31\), so:

\(\begin{equation*}

R^{2}=1-\dfrac{27.84}{48.31}=0.4237.

\end{equation*}\)

### Raw Residual

The **raw residual** is the difference between the actual response and the estimated value from the model. Remember that the variance is equal to the mean for a Poisson random variable. Therefore, we expect that the variances of the residuals are unequal. This can lead to difficulties in the interpretation of the raw residuals, yet it is still used. The formula for the raw residual is

\(\begin{equation*}

r_{i}=y_{i}-\exp\{\textbf{X}_{i}\beta\}.

\end{equation*}\)

### Pearson Residual

The **Pearson residual** corrects for the unequal variance in the raw residuals by dividing by the standard deviation. The formula for the Pearson residuals is

\(\begin{equation*}

p_{i}=\dfrac{r_{i}}{\sqrt{\hat{\phi}\exp\{\textbf{X}_{i}\beta\}}},

\end{equation*}\)

where

\(\begin{equation*}

\hat{\phi}=\dfrac{1}{n-p}\sum_{i=1}^{n}\frac{(y_{i}-\exp\{\textbf{X}_{i}\hat{\beta}\})^{2}}{\exp\{\textbf{X}_{i}\hat{\beta}\}}.

\end{equation*}\)

\(\hat{\phi}\) is a dispersion parameter to help control overdispersion.

### Deviance Residuals

**Deviance residuals** are also popular because the sum of squares of these residuals is the deviance statistic. The formula for the deviance residual is

\(\begin{equation*}

d_{i}=\texttt{sgn}(y_{i}-\exp\{\textbf{X}_{i}\hat{\beta}\})\sqrt{2\biggl\{y_{i}\log\biggl(\dfrac{y_{i}}{\exp\{\textbf{X}_{i}\hat{\beta}\}}\biggr)-(y_{i}-\exp\{\textbf{X}_{i}\hat{\beta}\})\biggr\}}.

\end{equation*}\)

The plots below show the Pearson residuals and deviance residuals versus the fitted values for the simulated example.

These plots appear to be good for a Poisson fit. Further diagnostic plots can also be produced and model selection techniques can be employed when faced with multiple predictors.

### Hat Values

The hat matrix serves the same purpose as in the case of linear regression - to measure the influence of each observation on the overall fit of the model. The hat values, \(h_{i,i}\), are the diagonal entries of the Hat matrix

\(\begin{equation*}

H=\textbf{W}^{1/2}\textbf{X}(\textbf{X}\textbf{W}\textbf{X})^{-1}\textbf{X}\textbf{W}^{1/2},

\end{equation*}\)

where **W** is an \(n\times n\) diagonal matrix with the values of $\exp\{\textbf{X}_{i}\hat{\beta}\}$ on the diagonal. As before, a hat value (leverage) is large if \(h_{i,i}>2p/n\).

### Studentized Residuals

Finally, we can also report Studentized versions of some of the earlier residuals. The **Studentized Pearson residuals** are given by

\(\begin{equation*}

sp_{i}=\dfrac{p_{i}}{\sqrt{1-h_{i,i}}}

\end{equation*}\)

and the **Studentized deviance residuals** are given by

\(\begin{equation*}

sd_{i}=\dfrac{d_{i}}{\sqrt{1-h_{i, i}}}.

\end{equation*}\)

To illustrate, the relevant Minitab output from the simulated example is:

## Fits and Diagnostics for Unusual Observations

Obs | y | Fit | SE Fit | 95% CI | Resid | Std Resid | Del Resid | HI | Cook's D |
---|---|---|---|---|---|---|---|---|---|

8 | 10.000 | 4.983 | 0.452 | (4.171, 5.952) | 1.974 | 2.02 | 2.03 | 0.040969 | 0.11 |

21 | 6.000 | 8.503 | 1.408 | (6.147, 11.763) | -0.907 | -1.04 | -1.02 | 0.233132 | 0.15 |

## Fits and Diagnostics for Unusual Observation

Obs | DFITS | ||
---|---|---|---|

8 | 0.474408 | R | |

21 | -0.540485 | X |

R large residual

X Unusual X

The default residuals in this output (set under Minitab's Regression Options) are deviance residuals, so observation 8 has a deviance residual of 1.974 and studentized deviance residual of 2.02, while observation 21 has leverage (h) of 0.233132.