Bayes factor

Editor-In-Chief: C. Michael Gibson, M.S., M.D. [1]

Overview

In statistics, the use of Bayes factors is a Bayesian alternative to classical hypothesis testing.

Given a model selection problem in which we have to choose between two models M₁ and M₂, on the basis of a data vector x. The Bayes factor K is given by

<math>K = \frac{p(x|M_1)}{p(x|M_2)}.</math>

where <math>p(x|M_i)</math> is called the marginal likelihood for model i. This is similar to a likelihood-ratio test, but instead of maximising the likelihood, Bayesians average it over the parameters. Generally, the models M₁ and M₂ will be parametrised by vectors of parameters θ₁ and θ₂; thus K is given by

<math>K = \frac{p(x|M_1)}{p(x|M_2)} = \frac{\int \,p(\theta_1|M_1)p(x|\theta_1, M_1)d\theta_1}{\int \,p(\theta_2|M_2)p(x|\theta_2, M_2)d\theta_2}.</math>

The logarithm of K is sometimes called the weight of evidence given by x for M₁ over M₂, measured in bits, nats, or bans, according to whether the logarithm is taken to base 2, base e, or base 10.

A value of K > 1 means that the data indicate that M₁ is more strongly supported by the data under consideration than M₂. Note that classical hypothesis testing gives one hypothesis (or model) preferred status (the 'null hypothesis'), and only considers evidence against it. Harold Jeffreys gave a scale for interpretation of K:

K	dB	Strength of evidence
< 1:1	< 0	Negative (supports M2)
1:1 to 3:1	0 to 5	Barely worth mentioning
3:1 to 10:1	5 to 10	Substantial
10:1 to 30:1	10 to 15	Strong
30:1 to 100:1	15 to 20	Very strong
>100:1	>20	Decisive

The second column gives the corresponding weights of evidence in decibans (tenths of a power of 10). According to I. J. Good a change in a weight of evidence of 1 deciban (ie a change in an odds ratio from evens to about 5:4) is about as finely as humans can reasonably perceive their degree of belief in a hypothesis in everyday use.

The use of Bayes factors or classical hypothesis testing takes place in the context of inference rather than decision-making under uncertainty. That is, we merely wish to find out which hypothesis is true, rather than actually making a decision on the basis of this information. Frequentist statistics draws a strong distinction between these two because classical hypothesis tests are not coherent in the Bayesian sense. Bayesian procedures, including Bayes factors, are coherent, so there is no need to draw such a distinction. Inference is then simply regarded as a special case of decision-making under uncertainty in which the resulting action is to report a value. In a decision-making context Bayesian statisticians might use a Bayes factor as part of making a choice, but would also combine it with a prior distribution and a loss function associated with making the wrong choice. In an inference context the loss function would take the form of a scoring rule. Use of a logarithmic score function for example, leads to the expected utility taking the form of the Kullback-Leibler divergence. If the logarithms are to the base 2 this is equivalent to Shannon information.

Example

Suppose we have a random variable which produces either a success or a failure. We want to compare a model M₁ where the probability of success is q = ½, and another model M₂ where q is completely unknown and we take a prior distribution for q which is uniform on [0,1]. We take a sample of 200, and find 115 successes and 85 failures. The likelihood is

<math>{{200 \choose 115}q^{115}(1-q)^{85}}.</math>

So we have

<math>P(X=115|M_1)={200 \choose 115}\left({1 \over 2}\right)^{200}=0.00595...,\,</math>

but

<math>P(X=115|M_2)=\int_{q=0}^1{200 \choose 115}q^{115}(1-q)^{85}dq = {1 \over 201} = 0.00497...\,.</math>

The ratio is then 1.197..., which is "barely worth mentioning" even if it points very slightly towards M₁.

This is not the same as a classical likelihood ratio test, which would have found the maximum likelihood estimate for q, namely ¹¹⁵⁄₂₀₀ = 0.575, and from that get a ratio of 0.1045..., and so pointing towards M₂. Alternatively, Edwards's "exchange rate" of two units of likelihood per degree of freedom suggests that <Math>M_2</math> is preferable (just) to <math>M_1</math>, as <math>0.1045\ldots = e^{-2.25\ldots}</math> and <math>2.25>2</math>: the extra likelihood compensates for the unknown parameter in <math>M_2</math>.

A frequentist hypothesis test of <math>M_1</math> (here considered as a null hypothesis) would have produced a more dramatic result, saying that M₁ could be rejected at the 5% significance level, since the probability of getting 115 or more successes from a sample of 200 if q = ½ is 0.0200..., and as a two-tailed test of getting a figure as extreme as or more extreme than 115 is 0.0400... Note that 115 is more than two standard deviations away from 100.

M₂ is a more complex model than M₁ because it has a free parameter which allows it to model the data more closely. The ability of Bayes factors to take this into account is a reason why Bayesian inference has been put forward as a theoretical justification for and generalisation of Occam's razor, reducing Type I errors.

See also

• Bayesian model comparison

• Marginal likelihood

External links

• Bayesian critique of classical hypothesis testing
• Why should clinicians care about Bayesian methods?