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*Not to be confused with general linear model or generalized least squares.*

In statistics, the **generalized linear model** (**GLM**) is a flexible generalization of ordinary linear regression that allows for response variables that have other than a normal distribution. The GLM generalizes linear regression by allowing the linear model to be related to the response variable via a **link function** and by allowing the magnitude of the variance of each measurement to be a function of its predicted value.

Generalized linear models were formulated by John Nelder and Robert Wedderburn as a way of unifying various other statistical models, including linear regression, logistic regression and Poisson regression.^{[1]} They proposed an iteratively reweighted least squares method for maximum likelihood estimation of the model parameters. Maximum-likelihood estimation remains popular and is the default method on many statistical computing packages. Other approaches, including Bayesian approaches and least squares fits to variance stabilized responses, have been developed.

## IntuitionEdit

Ordinary linear regression predicts the expected value of a given unknown quantity (the *response variable*, a random variable) as a linear combination of a set of observed values (*predictors*). This implies that a constant change in a predictor leads to a constant change in the response variable (i.e. a *linear-response model*). This is appropriate when the response variable has a normal distribution (intuitively, when a response variable can vary essentially indefinitely in either direction with no fixed "zero value", or more generally for any quantity that only varies by a relatively small amount, e.g. human heights).

However, these assumptions are inappropriate for many types of response variables. For example, in many cases when the response variable must be positive and can vary over a wide scale, constant input changes lead to geometrically varying rather than constantly varying output changes. As an example, a model that predicts that each decrease in 10 degrees Fahrenheit leads to 1,000 more people going to a given beach is unlikely to generalize well over both small beaches (e.g. those where the expected attendance was 50 at the lower temperature) and large beaches (e.g. those where the expected attendance was 10,000 at the lower temperature). An even worse problem is that, since the model also implies that a drop in 10 degrees leads 1,000 fewer people going to a given beach, a beach whose expected attendance was 50 at the higher temperature would now be predicted to have the impossible attendance value of -950! Logically, a more realistic model would instead predict a constant *rate* of increased beach attendance (e.g. an increase in 10 degrees leads to a doubling in beach attendance, and a drop in 10 degrees leads to a halving in attendance). Such a model is termed an *exponential-response model* (or *log-linear model*, since the logarithm of the response is predicted to vary linearly).

Similarly, a model that predicts a probability of making a yes/no choice (a Bernoulli variable) is even less suitable as a linear-response model, since probabilities are bounded on both ends (they must be between 0 and 1). Imagine, for example, a model that predicts the likelihood of a given person going to the beach as a function of temperature. A reasonable model might predict, for example, that a change in 10 degrees makes a person two times more or less likely to go to the beach. But what does "twice as likely" mean in terms of a probability? It cannot literally mean to double the probability value (e.g. 50% becomes 100%, 75% becomes 150%, etc.). Rather, it is the *odds* that are doubling: from 2:1 odds, to 4:1 odds, to 8:1 odds, etc. Such a model is a *log-odds model*.

Generalized linear models cover all these situations by allowing for response variables that have arbitrary distributions (rather than simply normal distributions), and for an arbitrary function of the response variable (the *link function*) to vary linearly with the predicted values (rather than assuming that the response itself must vary linearly). For example, the case above of predicted number of beach attendees would typically be modeled with a Poisson distribution and a log link, while the case of predicted probability of beach attendance would typically be modeled with a Bernoulli distribution (or binomial distribution, depending on exactly how the problem is phrased) and a log-odds (or *logit*) link function.

## OverviewEdit

In a generalized linear model (GLM), each outcome of the dependent variables, **Y**, is assumed to be generated from a particular distribution in the exponential family, a large range of probability distributions that includes the normal, binomial, Poisson and gamma distributions, among others. The mean, * μ*, of the distribution depends on the independent variables,

**X**, through:

- $ \operatorname{E}(\mathbf{Y}) = \boldsymbol{\mu} = g^{-1}(\mathbf{X}\boldsymbol{\beta}) $

where E(**Y**) is the expected value of **Y**; **X β** is the

*linear predictor*, a linear combination of unknown parameters,

*;*

**β***g*is the link function.

In this framework, the variance is typically a function, **V**, of the mean:

- $ \operatorname{Var}(\mathbf{Y}) = \operatorname{V}( \boldsymbol{\mu} ) = \operatorname{V}(g^{-1}(\mathbf{X}\boldsymbol{\beta})). $

It is convenient if **V** follows from the exponential family distribution, but it may simply be that the variance is a function of the predicted value.

The unknown parameters, * β*, are typically estimated with maximum likelihood, maximum quasi-likelihood, or Bayesian techniques.

## Model components Edit

The GLM consists of three elements:

- 1. A probability distribution from the exponential family.
- 2. A linear predictor
*η*=**X**.*β* - 3. A link function
*g*such that E(**Y**) =**μ**=*g*^{-1}(*η*).

### Probability distribution Edit

The **overdispersed exponential family** of distributions is a generalization of the exponential family and exponential dispersion model of distributions and includes those probability distributions, parameterized by $ \boldsymbol\theta $ and $ \tau $, whose density functions *f* (or probability mass function, for the case of a discrete distribution) can be expressed in the form

- $ f_Y(\mathbf{y} | \boldsymbol\theta, \tau) = h(\mathbf{y},\tau) \exp{\left(\frac{\mathbf{b}(\boldsymbol\theta)^{\rm T}\mathbf{T}(y) - A(\boldsymbol\theta)} {d(\tau)} \right)}. \,\! $

$ \tau $, called the *dispersion parameter*, typically is known and is usually related to the variance of the distribution. The functions $ h(\mathbf{y},\tau) $, $ \mathbf{b}(\boldsymbol\theta) $, $ \mathbf{T}(y) $, $ A(\boldsymbol\theta) $, and $ d(\tau) $ are known. Many, although not all, common distributions are in this family.

For scalar $ Y $ and $ \theta $, this reduces to

- $ f_Y(y | \theta, \tau) = h(y,\tau) \exp{\left(\frac{b(\theta)T(y) - A(\theta)}{d(\tau)} \right)}. \,\! $

$ \boldsymbol\theta $ is related to the mean of the distribution. If $ \mathbf{b}(\boldsymbol\theta) $ is the identity function, then the distribution is said to be in canonical form (or *natural form*). Note that any distribution can be converted to canonical form by rewriting $ \boldsymbol\theta $ as $ \boldsymbol\theta' $ and then applying the transformation $ \boldsymbol\theta = \mathbf{b}(\boldsymbol\theta') $. It is always possible to convert $ A(\boldsymbol\theta) $ in terms of the new parametrization, even if $ \mathbf{b}(\boldsymbol\theta') $ is not a one-to-one function; see comments in the page on the exponential family. If, in addition, $ \mathbf{T}(y) $ is the identity and $ \tau $ is known, then $ \boldsymbol\theta $ is called the *canonical parameter* (or *natural parameter*) and is related to the mean through

- $ \boldsymbol\mu = \operatorname{E}(\mathbf{Y}) = \nabla A(\boldsymbol\theta). \,\! $

For scalar $ Y $ and $ \theta $, this reduces to

- $ \mu = \operatorname{E}(Y) = A'(\theta). \,\! $

Under this scenario, the variance of the distribution can be shown to be^{[2]}

- $ \operatorname{Var}(\mathbf{Y}) = \nabla\nabla^{\rm T} A(\boldsymbol\theta) d(\tau). \,\! $

For scalar $ Y $ and $ \theta $, this reduces to

- $ \operatorname{Var}(Y) = A''(\theta) d(\tau). \,\! $

### Linear predictor Edit

The linear predictor is the quantity which incorporates the information about the independent variables into the model. The symbol *η* (Greek "eta") denotes a linear predictor. It is related to the expected value of the data (thus, "predictor") through the link function.

*η* is expressed as linear combinations (thus, "linear") of unknown parameters * β*. The coefficients of the linear combination are represented as the matrix of independent variables

**X**.

*η*can thus be expressed as

- $ \eta = \mathbf{X}\boldsymbol{\beta}.\, $

### Link function Edit

The link function provides the relationship between the linear predictor and the mean of the distribution function. There are many commonly used link functions, and their choice can be somewhat arbitrary. It can be convenient to match the domain of the link function to the range of the distribution function's mean.

When using a distribution function with a canonical parameter $ \theta $, the *canonical link* function is the function that expresses $ \theta $ in terms of $ \mu $, i.e. $ \theta = b(\mu) $. For the most common distributions, the mean $ \mu $ is one of the parameters in the standard form of the distribution's density function, and then $ b(\mu) $ is the function as defined above that maps the density function into its canonical form. When using the canonical link function, $ b(\mu) = \theta = \mathbf{X}\boldsymbol{\beta} $, which allows $ \mathbf{X}^{\rm T} \mathbf{Y} $ to be a sufficient statistic for $ \boldsymbol{\beta} $.

Following is a table of several exponential-family distributions in common use and the data they are typically used for, along with the canonical link functions and their inverses (sometimes referred to as the mean function, as done here).

Distribution | Support of distribution | Typical uses | Link name | Link function | Mean function |
---|---|---|---|---|---|

Normal | real: $ (-\infty,+\infty) $ | Linear-response data | Identity | $ \mathbf{X}\boldsymbol{\beta}=\mu\,\! $ | $ \mu=\mathbf{X}\boldsymbol{\beta}\,\! $ |

Exponential | real: $ (0,+\infty) $ | Exponential-response data, scale parameters | Inverse | $ \mathbf{X}\boldsymbol{\beta}=-\mu^{-1}\,\! $ | $ \mu=-(\mathbf{X}\boldsymbol{\beta})^{-1}\,\! $ |

Gamma | |||||

Inverse Gaussian | real: $ (0, +\infty) $ | Inverse squared | $ \mathbf{X}\boldsymbol{\beta}=-\mu^{-2}\,\! $ | $ \mu=(-\mathbf{X}\boldsymbol{\beta})^{-1/2}\,\! $ | |

Poisson | integer: $ [0,+\infty) $ | count of occurrences in fixed amount of time/space | Log | $ \mathbf{X}\boldsymbol{\beta}=\ln{(\mu)}\,\! $ | $ \mu=\exp{(\mathbf{X}\boldsymbol{\beta})}\,\! $ |

Bernoulli | integer: $ [0,1] $ | outcome of single yes/no occurrence | Logit | $ \mathbf{X}\boldsymbol{\beta}=\ln{\left(\frac{\mu}{1-\mu}\right)}\,\! $ | $ \mu=\frac{\exp{(\mathbf{X}\boldsymbol{\beta})}}{1 + \exp{(\mathbf{X}\boldsymbol{\beta})}} = \frac{1}{1 + \exp{(-\mathbf{X}\boldsymbol{\beta})}}\,\! $ |

Binomial | integer: $ [0,N] $ | count of # of "yes" occurrences out of N yes/no occurrences | |||

Categorical | integer: $ [0,K) $ | outcome of single K-way occurrence | |||

K-vector of integer: $ [0,1] $, where exactly one element in the vector has the value 1 | |||||

Multinomial | K-vector of integer: $ [0,N] $ | count of occurrences of different types (1 .. K) out of N total K-way occurrences |

In the cases of the exponential and gamma distributions, the domain of the canonical link function is not the same as the permitted range of the mean. In particular, the linear predictor may be negative, which would give an impossible negative mean. When maximizing the likelihood, precautions must be taken to avoid this. An alternative is to use a noncanonical link function.

Note also that in the case of the Bernoulli, binomial, categorical and multinomial distributions, the support of the distributions is not the same type of data as the parameter being predicted. In all of these cases, the predicted parameter is one or more probabilities, i.e. real numbers in the range $ [0,1] $. The resulting model is known as *logistic regression* (or *multinomial logistic regression* in the case that K-way rather than binary values are being predicted).

For the Bernoulli and binomial distributions, the parameter is a single probability, indicating the likelihood of occurrence of a single event. The Bernoulli still satisfies the basic condition of the generalized linear model in that, even though a single outcome will always be either 0 or 1, the *expected value* will nonetheless be a real-valued probability, i.e. the probability of occurrence of a "yes" (or 1) outcome. Similarly, in a binomial distribution, the expected value is *Np*, i.e. the expected proportion of "yes" outcomes will be the probability to be predicted.

For categorical and multinomial distributions, the parameter to be predicted is a *K*-vector of probabilities, with the further restriction that all probabilities must add up to 1. Each probability indicates the likelihood of occurrence of one of the *K* possible values. For the multinomial distribution, and for the vector form of the categorical distribution, the expected values of the elements of the vector can be related to the predicted probabilities similarly to the binomial and Bernoulli distributions.

## Fitting Edit

### Maximum likelihood Edit

The maximum likelihood estimates can be found using an iteratively reweighted least squares algorithm using either a Newton–Raphson method with updates of the form:

- $ \boldsymbol\beta^{(t+1)} = \boldsymbol\beta^{(t)} + \mathcal{J}^{-1}(\boldsymbol\beta^{(t)}) u(\boldsymbol\beta^{(t)}), $

where $ \mathcal{J}(\boldsymbol\beta^{(t)}) $ is the observed information matrix (the negative of the Hessian matrix) and $ u(\boldsymbol\beta^{(t)}) $ is the score function; or a Fisher's scoring method:

- $ \boldsymbol\beta^{(t+1)} = \boldsymbol\beta^{(t)} + \mathcal{I}^{-1}(\boldsymbol\beta^{(t)}) u(\boldsymbol\beta^{(t)}), $

where $ \mathcal{I}(\boldsymbol\beta^{(t)}) $ is the Fisher information matrix. Note that if the canonical link function is used, then they are the same.^{[3]}

### Bayesian methods Edit

In general, the posterior distribution cannot be found in closed form and so must be approximated, usually using Laplace approximations or some type of Markov chain Monte Carlo method such as Gibbs sampling.

## Examples Edit

### General linear models Edit

A possible point of confusion has to do with the distinction between generalized linear models and the general linear model, two broad statistical models. The general linear model may be viewed as a case of the generalized linear model with identity link. As most exact results of interest are obtained only for the general linear model, the general linear model has undergone a somewhat longer historical development. Results for the generalized linear model with non-identity link are asymptotic (tending to work well with large samples).

### Linear regression Edit

A simple, very important example of a generalized linear model (also an example of a general linear model) is linear regression. In linear regression, the use of the least-squares estimator is justified by the Gauss-Markov theorem, which does not assume that the distribution is normal.

From the perspective of generalized linear models, however, it is useful to suppose that the distribution function is the normal distribution with constant variance and the link function is the identity, which is the canonical link if the variance is known.

For the normal distribution, the generalized linear model has a closed form expression for the maximum-likelihood estimates, which is convenient. Most other GLMs lack closed form estimates.

### Binomial data Edit

When the response data, *Y*, are binary (taking on only values 0 and 1), the distribution function is generally chosen to be the Bernoulli distribution and the interpretation of *μ*_{i} is then the probability, *p*, of *Y*_{i} taking on the value one.

There are several popular link functions for binomial functions; the most typical is the canonical logit link:

- $ g(p) = \ln \left( { p \over 1-p } \right). $

GLMs with this setup are logistic regression models (or *logit models*).

In addition, the inverse of any continuous cumulative distribution function (CDF) can be used for the link since the CDF's range is $ [0,1] $, the range of the binomial mean. The normal CDF $ \Phi $ is a popular choice and yields the probit model. Its link is

- $ g(p) = \Phi^{-1}(p).\,\! $

The reason for the use of the probit model is that a constant scaling of the input variable to a normal CDF (which can be absorbed through equivalent scaling of all of the parameters) yields a function that is practically identical to the logit function, but probit models are more tractable in some situations than logit models. (In a Bayesian setting in which normally distributed prior distributions are placed on the parameters, the relationship between the normal priors and the normal CDF link function means that a probit model can be computed using Gibbs sampling, while a logit model generally cannot.)

The complementary log-log function log(−log(1−*p*)) may also be used. This link function is asymmetric and will often produce different results from the probit and logit link functions.^{[citation needed]}

The identity link is also sometimes used for binomial data to yield the linear probability model, but a drawback of this model is that the predicted probabilities can be greater than one or less than zero. In implementation it is possible to fix the nonsensical probabilities outside of $ [0,1] $, but interpreting the coefficients can be difficult. The model's primary merit is that near $ p = 0.5 $ it is approximately a linear transformation of the probit and logit―econometricians sometimes call this the Harvard model.

The variance function for binomial data is given by:

- $ \operatorname{Var}(Y_{i})= \tau\mu_{i} (1-\mu_{i})\,\! $

where the dispersion parameter *τ* is typically fixed at exactly one. When it is not, the resulting quasi-likelihood model often described as binomial with overdispersion or *quasibinomial*.

### Multinomial regressionEdit

The binomial case may be easily extended to allow for a multinomial distribution as the response (also, a Generalized Linear Model for counts, with a constrained total). There are two ways in which this is usually done:

#### Ordered responseEdit

If the response variable is an ordinal measurement, then one may fit a model function of the form:

- $ g(\mu_m) = \eta_m = \beta_0 + X_1 \beta_1 + \ldots + X_p \beta_p + \gamma_2 + \ldots + \gamma_m = \eta_1 + \gamma_2 + \ldots + \gamma_m \, $ where $ \mu_m = \mathrm{P}(Y \leq m) \, $.

for *m* > 2. Different links *g* lead to proportional odds models or ordered probit models.

#### Unordered responseEdit

If the response variable is a nominal measurement, or the data do not satisfy the assumptions of an ordered model, one may fit a model of the following form:

- $ g(\mu_m) = \eta_m = \beta_{m,0} + X_1 \beta_{m,1} + \ldots + X_p \beta_{m,p} \, $ where $ \mu_m = \mathrm{P}(Y = m \mid Y \in \{1,m\} ) \, $.

for *m* > 2. Different links *g* lead to multinomial logit or multinomial probit models. These are more general than the ordered response models, and more parameters are estimated.

### Count dataEdit

Another example of generalized linear models includes Poisson regression which models count data using the Poisson distribution. The link is typically the logarithm, the canonical link.

The variance function is proportional to the mean

- $ \operatorname{var}(Y_{i}) = \tau\mu_{i},\, $

where the dispersion parameter *τ* is typically fixed at exactly one. When it is not, the resulting quasi-likelihood model is often described as poisson with overdispersion or *quasipoisson*.

## ExtensionsEdit

### Edit

The standard GLM assumes that the observations are uncorrelated. Extensions have been developed to allow for correlation between observations, as occurs for example in longitudinal studies and clustered designs:

**Generalized estimating equations**(GEEs) allow for the correlation between observations without the use of an explicit probability model for the origin of the correlations, so there is no explicit likelihood. They are suitable when the random effects and their variances are not of inherent interest, as they allow for the correlation without explaining its origin. The focus is on estimating the average response over the population ("population-averaged" effects) rather than the regression parameters that would enable prediction of the effect of changing one or more components of**X**on a given individual. GEEs are usually used in conjunction with Huber-White standard errors.^{[4]}^{[5]}-
**Generalized linear mixed models**(GLMMs) are an extension to GLMs that includes random effects in the linear predictor, giving an explicit probability model that explains the origin of the correlations. The resulting "subject-specific" parameter estimates are suitable when the focus is on estimating the effect of changing one or more components of**X**on a given individual. GLMMs are also referred to as multilevel models and as mixed model. In general, fitting GLMMs is more computationally complex and intensive than fitting GEEs.

### Generalized additive modelsEdit

Generalized additive models (GAMs) are another extension to GLMs in which the linear predictor *η* is not restricted to be linear in the covariates **X** but is the sum of smoothing functions applied to the *x _{i}*s:

- $ \eta = \beta_0 + f_1(x_1) + f_2(x_2) + \ldots \,\! $

The smoothing functions *f _{i}* are estimated from the data. In general this requires a large number of data points and is computationally intensive.

^{[6]}

^{[7]}

## Confusion with general linear modelsEdit

The term "generalized linear model", and especially its abbreviation GLM, can be confused with general linear model. John Nelder has expressed regret about this in a conversation with Stephen Senn:

Senn: I must confess to having some confusion when I was a young statistician between general linear models and generalized linear models. Do you regret the terminology?

Nelder: I think probably I do. I suspect we should have found some more fancy name for it that would have stuck and not been confused with the general linear model, although general and generalized are not quite the same. I can see why it might have been better to have thought of something else.^{[8]}

## See alsoEdit

- Comparison of general and generalized linear models
- Generalized linear array model
- Tweedie distributions
- GLIM (software)
- Natural exponential family

## Notes Edit

- ↑ Nelder, John (1972). Generalized Linear Models.
*Journal of the Royal Statistical Society. Series A (General)***135**(3): 370–384. - ↑ McCullagh and Nelder (1989), Chapter 2.
- ↑ McCullagh and Nelder (1989), Page 43.
- ↑ Zeger, Scott L., Liang, Kung-Yee; Albert, Paul S. (1988). Models for Longitudinal Data: A Generalized Estimating Equation Approach.
*Biometrics***44**(4): 1049–1060. - ↑ Hardin, James; Hilbe, Joseph (2003).
*Generalized Estimating Equations*, London: Chapman and Hall/CRC. - ↑ Hastie, T. J. (1990).
*Generalized Additive Models*, Chapman & Hall/CRC. - ↑ Wood, Simon (2006).
*Generalized Additive Models: An Introduction with R*, Chapman & Hall/CRC. - ↑
Senn, Stephen (2003). A conversation with John Nelder.
*Statistical Science***18**(1): 118–131.

## ReferencesEdit

- McCullagh, Peter; Nelder, John (1989).
*Generalized Linear Models, Second Edition*, Boca Raton: Chapman and Hall/CRC. - Henrik Madsen and Poul Thyregod (2011).
*Introduction to General and Generalized Linear Models*, Chapman & Hall/CRC.

## Further readingEdit

- Dobson, A.J.; Barnett, A.G. (2008).
*Introduction to Generalized Linear Models*, 3rd, Boca Raton, FL: Chapman and Hall/CRC. - Hardin, James; Hilbe, Joseph (2007).
*Generalized Linear Models and Extensions*, 2nd, College Station: Stata Press.

## External linksEdit

- Systems Analysis, Modelling and Prediction (SAMP), University of Oxford
- John Nelder FRS
- Royal Society citation for Nelder

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