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Conjugate prior

 
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In Bayesian probability theory, a class of prior probability distributions p(θ) is said to be conjugate to a class of likelihood functions p(x|θ) if the resulting posterior distributions p(θ|x) are in the same family as p(θ); the prior and posterior are then called conjugate distributions, and the prior is called a conjugate prior for the likelihood. For example, the Gaussian family is conjugate to itself (or self-conjugate) with respect to a Gaussian likelihood function: if the likelihood function is Gaussian, choosing a Gaussian prior over the mean will ensure that the posterior distribution is also Gaussian. The concept, as well as the term "conjugate prior", were introduced by Howard Raiffa and Robert Schlaifer in their work on Bayesian decision theory.[1] A similar concept had been discovered independently by George Alfred Barnard.[2]

Consider the general problem of inferring a distribution for a parameter θ given some datum or data x. From Bayes' theorem, the posterior distribution is calculated from the prior p(θ) and the likelihood function \theta \mapsto p(x\mid\theta)\! as

p(\theta|x) = \frac{p(x|\theta) \, p(\theta)} {\int p(x|\theta) \, p(\theta) \, d\theta}. \!

Let the likelihood function be considered fixed; the likelihood function is usually well-determined from a statement of the data-generating process. It is clear that different choices of the prior distribution p(θ) may make the integral more or less difficult to calculate, and the product p(x|θ) × p(θ) may take one algebraic form or another. For certain choices of the prior, the posterior has the same algebraic form as the prior (generally with different parameters). Such a choice is a conjugate prior.

A conjugate prior is an algebraic convenience, giving a closed-form expression for the posterior: otherwise a difficult numerical integration may be necessary. Further, conjugate priors may give intuition, by more transparently showing how a likelihood function updates a distribution.

All members of the exponential family have conjugate priors. See Gelman et al.[3] for a catalog.

Contents

Example

For a random variable which is a Bernoulli trial with unknown probability of success q in [0,1], the usual conjugate prior is the beta distribution with

p(q=x) = {x^{\alpha-1}(1-x)^{\beta-1} \over \Beta(\alpha,\beta)}

where α and β are chosen to reflect any existing belief or information (α = 1 and β = 1 would give a uniform distribution) and Β(α, β) is the Beta function acting as a normalising constant.

In this context, α and β are called hyperparameters (parameters of the prior), to distinguish them from parameters of the underlying model (here q).

If we then sample this random variable and get s successes and f failures, we have

P(s,f|q=x) = {s+f \choose s} x^s(1-x)^f,
p(q=x|s,f) = {{{s+f \choose s} x^{s+\alpha-1}(1-x)^{f+\beta-1} / \Beta(\alpha,\beta)} \over \int_{y=0}^1 \left({s+f \choose s} y^{s+\alpha-1}(1-y)^{f+\beta-1} / \Beta(\alpha,\beta)\right) dy} = {x^{s+\alpha-1}(1-x)^{f+\beta-1} \over \Beta(s+\alpha,f+\beta)} ,

which is another Beta distribution with a simple change to the (hyper)parameters. This posterior distribution could then be used as the prior for more samples, with the hyperparameters simply adding each extra piece of information as it comes.

Interpretations

Analogy with eigenfunctions

Conjugate priors are analogous to eigenfunctions in operator theory, in that they are distributions on which the "conditioning operator" acts in a well-understood way, thinking of the process of changing from the prior to the posterior as an operator.

In both eigenfunctions and conjugate priors, there is a finite dimensional space which is preserved by the operator: the output is of the same form (in the same space) as the input. This greatly simplifies the analysis, as it otherwise considers an infinite dimensional space (space of all functions, space of all distributions).

However, the processes are only analogous, not identical: conditioning is not linear, as the space of distributions is not closed under linear combination, only convex combination, and the posterior is only of the same form as the prior, not a scalar multiple.

Just as one can easily analyze how a linear combination of eigenfunctions evolves under application of an operator (because, with respect to these functions, the operator is diagonalized), one can easily analyze how a convex combination of conjugate priors evolves under conditioning; this is called using a hyperprior, and corresponds to using a mixture density of conjugate priors, rather than a single conjugate prior.

Dynamical system

One can think of conditioning on conjugate priors as defining a kind of (discrete time) dynamical system: from a given set of hyperparameters, incoming data updates these hyperparameters, so one can see the change in hyperparameters as a kind of "time evolution" of the system, corresponding to "learning". Starting at different points yields different flows over time. This is again analogous with the dynamical system defined by a linear operator, but note that since different samples lead to different inference, this is not simply dependent on time, but rather on data over time.

Table of conjugate distributions

Let n denote the number of observations.

If the likelihood function belongs to the exponential family, then a conjugate prior exists, often also in the exponential family; see Exponential family: Conjugate distributions.

Discrete likelihood distributions

Likelihood Model parameters Conjugate prior distribution Prior hyperparameters Posterior hyperparameters
Bernoulli p (probability) Beta \alpha,\, \beta\! \alpha + \sum_{i=1}^n x_i,\, \beta + n - \sum_{i=1}^n x_i\!
Binomial p (probability) Beta \alpha,\, \beta\! \alpha + \sum_{i=1}^n x_i,\, \beta + \sum_{i=1}^nN_i - \sum_{i=1}^n x_i\!
Negative Binomial p (probability) Beta \alpha,\, \beta\! \alpha + rn,\, \beta + \sum_{i=1}^n x_i\!
Poisson λ (rate) Gamma k,\, \theta\! k+ \sum_{i=1}^n x_i,\ \frac {\theta} {\theta n + 1}\!
Poisson λ (rate) Gamma \alpha,\, \beta\! [4] \alpha + \sum_{i=1}^n x_i,\ \beta + n\!
Multinomial p (probability vector) Dirichlet \vec{\alpha}\! \vec{\alpha}+\sum_{i=1}^n\vec{x}^{\,(i)}\!
Geometric p0 (probability) Beta \alpha,\, \beta\! \alpha + n,\, \beta + \sum_{i=1}^n x_i\!

Continuous likelihood distributions

Likelihood Model parameters Conjugate prior distribution Prior hyperparameters Posterior hyperparameters
Uniform U(0,\theta)\! Pareto x_{m},\, k\! \max\{\,x_{(n)},x_{m}\},\, k+n\!
Exponential λ (rate) Gamma \alpha,\, \beta\! [4] \alpha+n,\, \beta+\sum_{i=1}^n x_i\!
Normal
with known variance σ2		 μ (mean) Normal \mu_0,\, \sigma_0^2\! \left.\left(\frac{\mu_0}{\sigma_0^2} + \frac{\sum_{i=1}^n x_i}{\sigma^2}\right)\right/\left(\frac{1}{\sigma_0^2} + \frac{n}{\sigma^2}\right),\, \left(\frac{1}{\sigma_0^2} + \frac{n}{\sigma^2}\right)^{-1}
Normal
with known precision τ		 μ (mean) Normal \mu_0,\, \tau_0\! \left.\left(\tau_0 \mu_0 + \tau \sum_{i=1}^n x_i\right)\right/(\tau_0 + n \tau),\, \tau_0 + n \tau
Normal
with known mean μ		 σ2 (variance) Scaled inverse chi-square \nu,\, \sigma_0^2\! \nu+n,\, \frac{\nu\sigma_0^2 + \sum_{i=1}^n (x_i-\mu)^2}{\nu+n}\!
Normal
with known mean μ		 τ (precision) Gamma \alpha,\, \beta\![4] \alpha + \frac{n}{2},\, \beta + \frac{\sum_{i=1}^n (x_i-\mu)^2}{2}\!
Normal
with known mean μ		 σ2 (variance) Inverse Gamma Distribution \mathbf{\alpha,\, \beta} [5] \mathbf{\alpha}+\frac{n}{2},\, \mathbf{\beta} + \frac{\sum_{i=1}^n{(x_i-\mu)^2}}{2}
Normal μ and σ2
Assuming exchangeability		 Normal-scaled inverse gamma \lambda ,\, \nu ,\, \alpha ,\, \beta \frac{\nu\lambda+n\bar{x}}{\nu+n} ,\, \nu+n,\, \alpha+\frac{n}{2} ,\, \beta + \tfrac{1}{2} \sum_{i=1}^n (x_i - \bar{x})^2 + \frac{n\nu}{n+\nu}\frac{(\bar{x}-\lambda)^2}{2} , where \bar{x} is the sample mean.
Normal μ and τ
Assuming exchangeability		 Normal-gamma \lambda,\, \gamma,\, \alpha,\, \beta\ \frac{\lambda \gamma+n\bar{x}}{\gamma+n},\, \gamma+n,\, \alpha+\frac{n}{2},\, \beta+\tfrac{1}{2} \sum_{i=1}^n (x_i - \bar{x})^2+\frac{n\gamma(\bar{x}-\lambda)^2}{2(n+\gamma)}, where \bar{x} is the sample mean.
Multivariate normal with known covariance matrix μ (mean vector) Multivariate normal \mathbf{\mu}_0,\, \Sigma_0 \left(\Sigma_0^{-1} + n\Sigma^{-1}\right)^{-1}\left( \Sigma_0^{-1}\mu_0 + n \Sigma^{-1} \bar{x} \right),\, \left(\Sigma_0^{-1} + n\Sigma^{-1}\right)^{-1}, where \bar{x} is the sample mean.
Multivariate normal with known precision matrix μ (mean vector) Multivariate normal \mathbf{\mu}_0,\, \Lambda_0 \left(\Lambda_0 + n\Lambda\right)^{-1}\left( \Lambda_0\mu_0 + n \Lambda \bar{x} \right),\, \left(\Lambda_0 + n\Lambda\right)^{-1}, where \bar{x} is the sample mean.
Multivariate normal with known mean Σ (covariance matrix) Inverse-Wishart \kappa ,\, \Psi n+\kappa ,\, \Psi + \sum_{i=1}^n (x_i - \mu) (x_i - \mu)^T
Multivariate normal with known mean Λ (precision matrix) Wishart
Multivariate normal μ (mean vector) and Σ (covariance matrix) Normal-Inverse-Wishart distribution \lambda ,\, \nu ,\, \kappa ,\, \Psi \frac{n\bar{x}+\nu\lambda}{n+\nu} ,\, n+\nu,\, n+\kappa ,\, \Psi + \sum_{i=1}^n (x_i - \bar{x}) (x_i - \bar{x})^T + \frac{n\nu}{n+\nu}(\bar{x}-\lambda)(\bar{x}-\lambda)^T , where \bar{x} is the sample mean
Multivariate normal μ (mean vector) and Λ (precision matrix) Normal-Wishart \kappa_0,\, \mathbf{\mu}_0,\, \nu_0,\, \Lambda_0 (\kappa_0 + n),\, \frac{\kappa_0}{\kappa_0 + n} \mathbf{\mu}_0 + \frac{n}{\kappa_0 + n} \bar{x},\, (\nu_0 + n),\, \left( \Lambda_0^{-1} + C + \frac{\kappa_0 n}{\kappa_0 + n} (\bar{x} - \mathbf{\mu}_0) (\bar{x} - \mathbf{\mu}_0)^T \right)^{-1} where \bar{x} is the sample mean and C = \sum_{i=1}^n (x_i - \bar{x}) (x_i - \bar{x})^T.
Pareto k (shape) Gamma \alpha,\, \beta\! \alpha+n,\, \beta+\sum_{i=1}^n \ln\frac{x_i}{x_{\mathrm{m}}}\!
Pareto xm (location) Pareto x_0,\, k_0\! x_0,\, k_0-kn \! where k_0 > kn\!.
Gamma
with known shape α		 β (inverse scale) Gamma \alpha_0,\, \beta_0\! \alpha_0+n\alpha,\, \beta_0+\sum_{i=1}^n x_i\!
Inverse Gamma
with known shape α		 β (inverse scale) Gamma \alpha_0,\, \beta_0\! \alpha_0+n\alpha,\, \beta_0+\sum_{i=1}^n \frac{1}{x_i}\!
Gamma [6] α (shape), β (inverse scale) \frac{1}{Z} \frac{p^{\alpha-1} e^{-\beta q}}{\Gamma(\alpha)^r \beta^{-\alpha s}} p,\, q,\, r,\, s \! p \prod_{i=1}^n x_i,\, q + \sum_{i=1}^n x_i,\, r + n,\, s + n \!

References

  1. ^ Howard Raiffa and Robert Schlaifer. Applied Statistical Decision Theory. Division of Research, Graduate School of Business Administration, Harvard University, 1961.
  2. ^ Jeff Miller et al. Earliest Known Uses of Some of the Words of Mathematics, "conjugate prior distributions". Electronic document, revision of November 13, 2005, retrieved December 2, 2005.
  3. ^ Andrew Gelman, John B. Carlin, Hal S. Stern, and Donald B. Rubin. Bayesian Data Analysis, 2nd edition. CRC Press, 2003. ISBN 1-58488-388-X.
  4. ^ a b c β is rate or inverse scale. In parameterization of Gamma distribution,θ = 1/β and k = α.
  5. ^ In terms of the Inverse Gamma Distribution, β is a Scale parameter
  6. ^ Fink, D. 1995 A Compendium of Conjugate Priors. In progress report: Extension and enhancement of methods for setting data quality objectives. (DOE contract 95‑831).

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