In mathematical statistics, the Fisher information (sometimes simply called information) is a way of measuring the amount of information that an observable random variable X carries about an unknown parameter θ upon which the probability of X depends. Formally, it is the variance of the score, or the expected value of the observed information. In Bayesian statistics, the asymptotic distribution of the posterior mode depends on the Fisher information and not on the prior (according to the Bernstein–von Mises theorem, which was anticipated by Laplace for exponential families). The role of the Fisher information in the asymptotic theory of maximum-likelihood estimation was emphasized by the statistician R.A. Fisher (following some initial results by F. Y. Edgeworth). The Fisher information is also used in the calculation of the Jeffreys prior, which is used in Bayesian statistics.
The Fisher-information matrix is used to calculate the covariance matrices associated with maximum-likelihood estimates. It can also be used in the formulation of test statistics, such as the Wald test.
- 1 History
- 2 Definition
- 3 Matrix form
- 4 Properties
- 5 Applications
- 6 Relation to relative entropy
- 7 Distinction from the Hessian of the entropy
- 8 See also
- 9 Notes
- 10 References
- 11 External links
The Fisher information was discussed by several early statisticians, notably F. Y. Edgeworth. For example, Savage says: "In it [Fisher information], he [Fisher] was to some extent anticipated (Edgeworth 1908–9 esp. 502, 507–8, 662, 677–8, 82–5 and references he [Edgeworth] cites including Pearson and Filon 1898 [. . .])." There are a number of early historical sources and a number of reviews of this early work.
The Fisher information is a way of measuring the amount of information that an observable random variable X carries about an unknown parameter θ upon which the probability of X depends. The probability function for X, which is also the likelihood function for θ, is a function f(X; θ); it is the probability mass (or probability density) of the random variable X conditional on the value of θ. The partial derivative with respect to θ of the natural logarithm of the likelihood function is called the score.
The second moment is called the Fisher information:
where, for any given value of θ, the expression E[...|θ] denotes the conditional expectation over values for X with respect to the probability function f(x; θ) given θ. Note that . A random variable carrying high Fisher information implies that the absolute value of the score is often high. The Fisher information is not a function of a particular observation, as the random variable X has been averaged out.
If log f(x; θ) is twice differentiable with respect to θ, and under certain regularity conditions, then the Fisher information may also be written as
Thus, the Fisher information is the negative of the expectation of the second derivative with respect to θ of the natural logarithm of f. Information may be seen to be a measure of the "curvature" of the support curve near the maximum likelihood estimate of θ. A "blunt" support curve (one with a shallow maximum) would have a low negative expected second derivative, and thus low information; while a sharp one would have a high negative expected second derivative and thus high information.
Information is additive, in that the information yielded by two independent experiments is the sum of the information from each experiment separately:
This result follows from the elementary fact that if random variables are independent, the variance of their sum is the sum of their variances. In particular, the information in a random sample of size n is n times that in a sample of size 1, when observations are independent and identically distributed.
The information provided by a sufficient statistic is the same as that of the sample X. This may be seen by using Neyman's factorization criterion for a sufficient statistic. If T(X) is sufficient for θ, then
for some functions g and h. See sufficient statistic for a more detailed explanation. The equality of information then follows from the following fact:
which follows from the definition of Fisher information, and the independence of h(X) from θ. More generally, if T = t(X) is a statistic, then
Informal derivation of the Cramér–Rao bound
The Cramér–Rao bound states that the inverse of the Fisher information is a lower bound on the variance of any unbiased estimator of θ. Van Trees (1968) and Frieden (2004) provide the following method of deriving the Cramér–Rao bound, a result which describes use of the Fisher information, informally:
Consider an unbiased estimator . Mathematically, we write
The likelihood function f(X; θ) describes the probability that we observe a given sample x given a known value of θ. If f is sharply peaked with respect to changes in θ, it is easy to intuit the "correct" value of θ given the data, and hence the data contains a lot of information about the parameter. If the likelihood f is flat and spread-out, then it would take many, many samples of X to estimate the actual "true" value of θ. Therefore, we would intuit that the data contain much less information about the parameter.
Now, we differentiate the unbiased-ness condition above to get
We now make use of two facts. The first is that the likelihood f is just the probability of the data given the parameter. Since it is a probability, it must be normalized, implying that
Second, we know from basic calculus that
Using these two facts in the above let us write
Factoring the integrand gives
If we square the equation, the Cauchy–Schwarz inequality lets us write
The right-most factor is defined to be the Fisher Information
The left-most factor is the expected mean-squared error of the estimator θ^, since
Notice that the inequality tells us that, fundamentally,
In other words, the precision to which we can estimate θ is fundamentally limited by the Fisher Information of the likelihood function.
Single-parameter Bernoulli experiment
A Bernoulli trial is a random variable with two possible outcomes, "success" and "failure", with success having a probability of θ. The outcome can be thought of as determined by a coin toss, with the probability of heads being θ and the probability of tails being 1 − θ.
The Fisher information contained in n independent Bernoulli trials may be calculated as follows. In the following, A represents the number of successes, B the number of failures, and n = A + B is the total number of trials.
(1) defines Fisher information. (2) invokes the fact that the information in a sufficient statistic is the same as that of the sample itself. (3) expands the natural logarithm term and drops a constant. (4) and (5) differentiate with respect to θ. (6) replaces A and B with their expectations. (7) is algebra.
The end result, namely,
The FIM is a N × N positive semidefinite symmetric matrix, defining a Riemannian metric on the N-dimensional parameter space, thus connecting Fisher information to differential geometry. In that context, this metric is known as the Fisher information metric, and the topic is called information geometry.
Under certain regularity conditions, the Fisher Information Matrix may also be written as
The metric is interesting in several ways; it can be derived as the Hessian of the relative entropy; it can be understood as a metric induced from the Euclidean metric, after appropriate change of variable; in its complex-valued form, it is the Fubini–Study metric.
We say that two parameters θi and θj are orthogonal if the element of the ith row and jth column of the Fisher information matrix is zero. Orthogonal parameters are easy to deal with in the sense that their maximum likelihood estimates are independent and can be calculated separately. When dealing with research problems, it is very common for the researcher to invest some time searching for an orthogonal parametrization of the densities involved in the problem.
Multivariate normal distribution
Note that a special, but very common, case is the one where Σ(θ) = Σ, a constant. Then
In this case the Fisher information matrix may be identified with the coefficient matrix of the normal equations of least squares estimation theory.
Another special case is that the mean and covariance depends on two different vector parameters, say, β and θ. This is especially popular in the analysis of spatial data, which uses a linear model with correlated residuals. We have
The proof of this special case is given in literature. Using the same technique in this paper, it's not difficult to prove the original result.
The Fisher information depends on the parametrization of the problem. If θ and η are two scalar parametrizations of an estimation problem, and θ is a continuously differentiable function of η, then
where and are the Fisher information measures of η and θ, respectively.
In the vector case, suppose and are k-vectors which parametrize an estimation problem, and suppose that is a continuously differentiable function of , then,
where the (i, j)th element of the k × k Jacobian matrix is defined by
and where is the matrix transpose of .
In information geometry, this is seen as a change of coordinates on a Riemannian manifold, and the intrinsic properties of curvature are unchanged under different parametrization. In general, the Fisher information matrix provides a Riemannian metric (more precisely, the Fisher-Rao metric) for the manifold of thermodynamic states, and can be used as an information-geometric complexity measure for a classification of phase transitions, e.g., the scalar curvature of the thermodynamic metric tensor diverges at (and only at) a phase transition point.
In the thermodynamic context, the Fisher information matrix is directly related to the rate of change in the corresponding order parameters. In particular, such relations identify second-order phase transitions via divergences of individual elements of the Fisher information matrix.
Optimal design of experiments
Fisher information is widely used in optimal experimental design. Because of the reciprocity of estimator-variance and Fisher information, minimizing the variance corresponds to maximizing the information.
When the linear (or linearized) statistical model has several parameters, the mean of the parameter-estimator is a vector and its variance is a matrix. The inverse matrix of the variance-matrix is called the "information matrix". Because the variance of the estimator of a parameter vector is a matrix, the problem of "minimizing the variance" is complicated. Using statistical theory, statisticians compress the information-matrix using real-valued summary statistics; being real-valued functions, these "information criteria" can be maximized.
Traditionally, statisticians have evaluated estimators and designs by considering some summary statistic of the covariance matrix (of a mean–unbiased estimator), usually with positive real values (like the determinant or matrix trace). Working with positive real-numbers brings several advantages: If the estimator of a single parameter has a positive variance, then the variance and the Fisher information are both positive real numbers; hence they are members of the convex cone of nonnegative real numbers (whose nonzero members have reciprocals in this same cone). For several parameters, the covariance-matrices and information-matrices are elements of the convex cone of nonnegative-definite symmetric matrices in a partially ordered vector space, under the Loewner (Löwner) order. This cone is closed under matrix-matrix addition, under matrix-inversion, and under the multiplication of positive real-numbers and matrices. An exposition of matrix theory and the Loewner-order appears in Pukelsheim.
The traditional optimality-criteria are the information-matrix's invariants; algebraically, the traditional optimality-criteria are functionals of the eigenvalues of the (Fisher) information matrix: see optimal design.
Jeffreys prior in Bayesian statistics
Relation to relative entropy
Fisher information is related to relative entropy. Consider a family of probability distributions where is a parameter which lies in a range of values. Then the relative entropy, or Kullback–Leibler divergence, between two distributions in the family can be written as
And the fisher information is:
If we consider fixed, the relative entropy between two distributions of the same family is minimized at . For close to one may expand the previous expression in a series up to second order:
Thus the Fisher information represents the curvature of the relative entropy.
Distinction from the Hessian of the entropy
In certain cases, the Fisher Information matrix is the negative of the Hessian of the Shannon entropy.[clarification needed] The cases where this explicitly holds are given below. A distribution's Shannon entropy
has as the negative of the entry of its Hessian:
In contrast, the entry of the Fisher information matrix is
The difference between the negative Hessian and the Fisher information is[clarification needed]
In particular, the Fisher Information matrix will be the same as the negative of the Hessian of the entropy in situations where is zero for all i, j, X, and θ. For instance, a two-dimensional example that makes the two equal is
where g1(X), g2(X), and g3(X) are probability distributions.
A one-dimensional example where the Fisher Information differs from the negative Hessian is . In this case, the entropy H is independent of the distribution mean θ. Thus, the second derivative of the entropy with respect to θ is zero. However, for the Fisher information, we have
- Observed information
- Fisher information metric
- Formation matrix
- Information geometry
- Jeffreys prior
- Cramér–Rao bound
Other measures employed in information theory:
- Lehmann and Casella, p. 115
- Lucien Le Cam (1986) Asymptotic Methods in Statistical Decision Theory: Pages 336 and 618–621 (von Mises and Bernstein).
- Savage (1976)
- Savage(1976), page 156
- Edgeworth (September 1908, December 1908)
- Pratt (1976)
- Stigler (1978, 1986, 1999)
- Hald (1998, 1999)
- Suba Rao. "Lectures on statistical inference".
- Lehmann and Casella, eq. (2.5.16).
- Mardia, K. V.; Marshall, R. J. (1984). "Maximum likelihood estimation of models for residual covariance in spatial regression". Biometrika 71 (1): 135–46. doi:10.1093/biomet/71.1.135.
- Lehmann and Casella, eq. (2.5.11).
- Lehmann and Casella, eq. (2.6.16)
- Janke, W.; Johnston, D. A.; Kenna, R. (2004). "Information Geometry and Phase Transitions". Physica A 336 (1–2): 181. doi:10.1016/j.physa.2004.01.023.
- Prokopenko, M. (2011). "Relating Fisher information to order parameters". Physical Review E 84: 041116. doi:10.1103/PhysRevE.84.041116.
- Friedrick Pukelsheim, Optimal Design of Experiments, 1993
- Bayesian theory, Jose M. Bernardo and Adrian FM. Smith, John Wiley & Sons, 1994
- Gourieroux (1995), page 87
- Edgeworth, F. Y. (Sep 1908). "On the Probable Errors of Frequency-Constants". Journal of the Royal Statistical Society 71 (3): 499–512. doi:10.2307/2339293. JSTOR 2339293.
- Edgeworth, F. Y. (Dec 1908). "On the Probable Errors of Frequency-Constants". Journal of the Royal Statistical Society 71 (4): 651–678. doi:10.2307/2339378. JSTOR 2339378.
- Frieden, B. Roy (2004) Science from Fisher Information: A Unification. Cambridge Univ. Press. ISBN 0-521-00911-1.
- Hald, A. (May 1999). "On the History of Maximum Likelihood in Relation to Inverse Probability and Least Squares". Statistical Science 14 (2): 214–222. doi:10.1214/ss/1009212248. JSTOR 2676741.
- Hald, A. (1998). A History of Mathematical Statistics from 1750 to 1930. New York: Wiley. ISBN 0-471-17912-4.
- Lehmann, E. L.; Casella, G. (1998). Theory of Point Estimation (2nd ed.). Springer. ISBN 0-387-98502-6.
- Le Cam, Lucien (1986). Asymptotic Methods in Statistical Decision Theory. Springer-Verlag. ISBN 0-387-96307-3.
- Pratt, John W. (May 1976). "F. Y. Edgeworth and R. A. Fisher on the Efficiency of Maximum Likelihood Estimation". The Annals of Statistics 4 (3): 501–514. doi:10.1214/aos/1176343457. JSTOR 2958222.
- Leonard J. Savage (May 1976). "On Rereading R. A. Fisher". The Annals of Statistics 4 (3): 441–500. doi:10.1214/aos/1176343456. JSTOR 2958221.
- Schervish, Mark J. (1995). "Section 2.3.1". Theory of Statistics. New York: Springer. ISBN 0-387-94546-6.
- Stephen Stigler (1986). The History of Statistics: The Measurement of Uncertainty before 1900. Harvard University Press. ISBN 0-674-40340-1.[page needed]
- Stephen M. Stigler (1978). "Francis Ysidro Edgeworth, Statistician". Journal of the Royal Statistical Society, Series A 141 (3): 287–322. doi:10.2307/2344804. JSTOR 2344804.
- Stephen Stigler (1999). Statistics on the Table: The History of Statistical Concepts and Methods. Harvard University Press. ISBN 0-674-83601-4.[page needed]
- Van Trees, H. L. (1968). Detection, Estimation, and Modulation Theory, Part I. New York: Wiley. ISBN 0-471-09517-6.
- Fisher4Cast: a Matlab, GUI-based Fisher information tool for research and teaching, primarily aimed at cosmological forecasting applications.
- FandPLimitTool a GUI-based software to calculate the Fisher information and CRLB with application to single-molecule microscopy.
-  lectures on statistical inference