Ancillary statistic

In statistics, ancillarity is a property of a statistic computed on a sample dataset in relation to a parametric model of the dataset. An ancillary statistic has the same distribution regardless of the value of the parameters and thus provides no information about them. ^{[1] [2] [3]} It is opposed to the concept of a complete statistic which contains no ancillary information. It is closely related to the concept of a sufficient statistic which contains all of the information that the dataset provides about the parameters.

A ancillary statistic is a specific case of a pivotal quantity that is computed only from the data and not from the parameters. They can be used to construct prediction intervals. They are also used in connection with Basu's theorem to prove independence between statistics. ^[4]

This concept was first introduced by Ronald Fisher in the 1920s, ^[5] but its formal definition was only provided in 1964 by Debabrata Basu. ^{[6] [7]}

Examples

Suppose X₁, ..., X_n are independent and identically distributed, and are normally distributed with unknown expected value μ and known variance 1. Let

${\displaystyle {\overline {X}}_{n}={\frac {X_{1}+\,\cdots \,+X_{n}}{n}}}$

be the sample mean.

The following statistical measures of dispersion of the sample

• Range: max(X₁, ..., X_n) − min(X₁, ..., X_n)
• Interquartile range: Q₃−Q₁
• Sample variance:

${\displaystyle {\hat {\sigma }}^{2}:=\,{\frac {\sum \left(X_{i}-{\overline {X}}\right)^{2}}{n}}}$

are all ancillary statistics, because their sampling distributions do not change as μ changes. Computationally, this is because in the formulas, the μ terms cancel – adding a constant number to a distribution (and all samples) changes its sample maximum and minimum by the same amount, so it does not change their difference, and likewise for others: these measures of dispersion do not depend on location.

Conversely, given i.i.d. normal variables with known mean 1 and unknown variance σ², the sample mean ${\displaystyle {\overline {X}}}$ is not an ancillary statistic of the variance, as the sampling distribution of the sample mean is N(1, σ²/n), which does depend on σ² – this measure of location (specifically, its standard error) depends on dispersion. ^[8]

In location-scale families

In a location family of distributions, ${\displaystyle (X_{1}-X_{n},X_{2}-X_{n},\dots ,X_{n-1}-X_{n})}$ is an ancillary statistic.

In a scale family of distributions, ${\displaystyle \left({\frac {X_{1}}{X_{n}}},{\frac {X_{2}}{X_{n}}},\dots ,{\frac {X_{n-1}}{X_{n}}}\right)}$ is an ancillary statistic.

In a location-scale family of distributions, ${\displaystyle ({\frac {X_{1}-X_{n}}{S}},{\frac {X_{2}-X_{n}}{S}},\dots ,{\frac {X_{n-1}-X_{n}}{S}})}$, where ${\displaystyle S^{2}}$ is the sample variance, is an ancillary statistic. ^{[3] [9]}

In recovery of information

It turns out that, if ${\displaystyle T_{1}}$ is a non-sufficient statistic and ${\displaystyle T_{2}}$ is ancillary, one can sometimes recover all the information about the unknown parameter contained in the entire data by reporting ${\displaystyle T_{1}}$ while conditioning on the observed value of ${\displaystyle T_{2}}$. This is known as conditional inference. ^[3]

For example, suppose that ${\displaystyle X_{1},X_{2}}$ follow the ${\displaystyle N(\theta ,1)}$ distribution where ${\displaystyle \theta }$ is unknown. Note that, even though ${\displaystyle X_{1}}$ is not sufficient for ${\displaystyle \theta }$ (since its Fisher information is 1, whereas the Fisher information of the complete statistic ${\displaystyle {\overline {X}}}$ is 2), by additionally reporting the ancillary statistic ${\displaystyle X_{1}-X_{2}}$, one obtains a joint distribution with Fisher information 2. ^[3]

Ancillary complement

Given a statistic T that is not sufficient, an ancillary complement is a statistic U that is ancillary and such that (T, U) is sufficient. ^[2] Intuitively, an ancillary complement "adds the missing information" (without duplicating any).

The statistic is particularly useful if one takes T to be a maximum likelihood estimator, which in general will not be sufficient; then one can ask for an ancillary complement. In this case, Fisher argues that one must condition on an ancillary complement to determine information content: one should consider the Fisher information content of T to not be the marginal of T, but the conditional distribution of T, given U: how much information does Tadd? This is not possible in general, as no ancillary complement need exist, and if one exists, it need not be unique, nor does a maximum ancillary complement exist.

Example

In baseball, suppose a scout observes a batter in N at-bats. Suppose (unrealistically) that the number N is chosen by some random process that is independent of the batter's ability – say a coin is tossed after each at-bat and the result determines whether the scout will stay to watch the batter's next at-bat. The eventual data are the number N of at-bats and the number X of hits: the data (X, N) are a sufficient statistic. The observed batting average X/N fails to convey all of the information available in the data because it fails to report the number N of at-bats (e.g., a batting average of 0.400, which is very high, based on only five at-bats does not inspire anywhere near as much confidence in the player's ability than a 0.400 average based on 100 at-bats). The number N of at-bats is an ancillary statistic because

• It is a part of the observable data (it is a statistic), and
• Its probability distribution does not depend on the batter's ability, since it was chosen by a random process independent of the batter's ability.

This ancillary statistic is an ancillary complement to the observed batting average X/N, i.e., the batting average X/N is not a sufficient statistic, in that it conveys less than all of the relevant information in the data, but conjoined with N, it becomes sufficient.

See also

• Basu's theorem
• Prediction interval
• Group family
• Conditionality principle

Notes

1. Lehmann, E. L.; Scholz, F. W. (1992). "Ancillarity" (PDF). Lecture Notes-Monograph Series. Institute of Mathematical Statistics Lecture Notes - Monograph Series. 17: 32–51. doi:10.1214/lnms/1215458837. ISBN   0-940600-24-2. ISSN   0749-2170. JSTOR   4355624.
2. Ghosh, M.; Reid, N.; Fraser, D. A. S. (2010). "Ancillary statistics: A review". Statistica Sinica. 20 (4): 1309–1332. ISSN   1017-0405. JSTOR   24309506.
3. Mukhopadhyay, Nitis (2000). Probability and Statistical Inference. United States of America: Marcel Dekker, Inc. pp. 309–318. ISBN   0-8247-0379-0.
4. Dawid, Philip (2011), DasGupta, Anirban (ed.), "Basu on Ancillarity", Selected Works of Debabrata Basu, New York, NY: Springer, pp. 5–8, doi: 10.1007/978-1-4419-5825-9_2 , ISBN   978-1-4419-5825-9
5. Fisher, R. A. (1925). "Theory of Statistical Estimation". Mathematical Proceedings of the Cambridge Philosophical Society. 22 (5): 700–725. Bibcode:1925PCPS...22..700F. doi:10.1017/S0305004100009580. hdl: 2440/15186 . ISSN   0305-0041.
6. Basu, D. (1964). "Recovery of Ancillary Information". Sankhyā: The Indian Journal of Statistics, Series A (1961-2002). 26 (1): 3–16. ISSN   0581-572X. JSTOR   25049300.
7. Stigler, Stephen M. (2001), Ancillary history, Institute of Mathematical Statistics Lecture Notes - Monograph Series, Beachwood, OH: Institute of Mathematical Statistics, pp. 555–567, doi: 10.1214/lnms/1215090089 , ISBN   978-0-940600-50-8 , retrieved 2023-04-24
8. Buehler, Robert J. (1982). "Some Ancillary Statistics and Their Properties". Journal of the American Statistical Association. 77 (379): 581–589. doi:10.1080/01621459.1982.10477850. hdl: 11299/199392 . ISSN   0162-1459.
9. "Ancillary statistics" (PDF).