Stephen B. Vardeman
Iowa State University
Joanne R. Wendelberger
Los Alamos National Laboratory
Journal of Statistics Education Volume 13, Number 1 (2005), ww2.amstat.org/publications/jse/v13n1/vardeman.html
Copyright © 2005 by Stephen B. Vardeman and Joanne R. Wendelberger, all rights reserved. This text may be freely shared among individuals, but it may not be republished in any medium without express written consent from the authors and advance notification of the editor.
Key Words: Heteroscedastic; Method of moments; One-way model; Two-factor hierarchical model; Standard error of the mean; Variance component
Lemma 1 If Y1, Y2, ..., Yn are uncorrelated random variables with a common mean (say ) and possibly different variances , and
is their sample variance, then
Proof: First note that
Then observe that one may with no loss of generality assume that = 0. (The Yi and the have the same sample variance, and if necessary one could replace the Yi with Yi* above.) The assumption that the Yi are uncorrelated then implies that EYiYj for all . Since with mean 0, , the lemma is proved.
A referee has suggested that in many classroom proofs of Lemma 1, it will be best to write in the form and further suggests that a good exercise will often be to ask students to redo the proof without simplifying to the = 0 case. Notice that under the = 0 case assumption, the type of summation notation used may not be so important, in that in either notation it is immediate from the fact that EYiYj = 0 for all that . Not making use of the observation that one may reduce to the = 0 case requires using the facts that and , and being able to count that there are terms in in order to get the necessary cancellation of squared means. How it is easiest for students to see the counting fact from the type of summation notation used depends upon what has gone before in a course. In any case, we think that it is important to use the device of reducing to = 0 in classroom proofs, not simply because it is “elegant,” but more importantly because it foreshadows how the lemma can be applied in variance component estimation. (See the use of the fact that sample variances are unchanged by the addition of a common value to each element of a “data set” in our later discussion of estimation in an unbalanced two-factor nested design.)
Lemma 1 is very simple and arguably “obvious.” But it is not well known and provides a mathematically satisfying extension of the standard result. Further, it can be applied to good effect in important teaching and data analysis contexts.
Note, for example, that under the hypotheses of the lemma
So is potentially a sensible estimator of (at least where the relative precisions of the Yi are unknown) and
functions as a standard error for in the potentially heteroscedastic case of the lemma as well as the more familiar iid situation. This is a kind of “robustness” result for the usual standard error of the sample mean and appears as Problem 2.2.3 on page 52 of Stapleton (1995) without explicit mention of Lemma 1. (This is the only reference known to the authors that even hints at Lemma 1.)
We proceed to illustrate that the lemma has important additional uses beyond this most obvious one.
But it is possible to use Lemma 1 to produce simple/from-first-principles estimators based on (even) unbalanced data under linear random effects models (and in the process demystify the problem of estimation in these models). This is because the lemma shows expected sample variances of appropriate sample average observations to be easily-identified linear combinations of variance components. We first illustrate in the general context of the one-way random effects model.
That is, suppose that for i = 1, 2, ..., I, and j = 1, 2, ..., ni
for some constant, with mean 0 and variance , with mean 0 and variance , and all of the and uncorrelated. We may apply the foregoing to the uncorrelated sample means
The unweighted mean of sample means
is an unbiased estimator of with
If we write
by Lemma 1, this sample variance (of sample means) has expected value
So in light of (1) and (2), a standard error for the unbiased estimator of is
regardless of whether or not the data are balanced.
The authors’ original motivation for considering applications of Lemma 1 (and in particular, standard error (3)) in the one-way context was a calibration problem where represented a day-to-day variance component in the measurement of a standard, represented a within-day variance component, and constraints in the measurement process led to an error analysis based on the average values. The approach was also applicable in another situation, where analysis of summary data was required, and the sample sizes (and individual observations Xij) were not available.
What is more, where the sample sizes and within-group sample variances are available, it is easy to use Lemma 1 to motivate simple estimators of the variance components. Let
be the usual pooled sample variance (or mean squared error). This has mean . In light of equation (2),
which suggests the simple estimators of variance components
which appear, for example, in Rao (1997, page 20) and Cox and Solomon (2003, pages 74-76).
Figure 1: Schematic of a particular unbalanced two-factor hierarchical data structure
That is, with
for some constant, the with mean 0 and variance , the with mean 0 and variance , the with mean 0 and variance , and all of the , , and uncorrelated. Let
and define sample means
and unweighted means of these
and the unweighted mean of these
We consider estimators of the variance components , , and based on the sample variances (of unweighted sample means)
To begin, as always, the usual pooled sample variance
serves as an unbiased estimator of . Note then that using the usual notation for averages of ’s
and that S12 is not only the sample variance of and , but also of and (using the same reasoning applied in the proof of Lemma 1 to reduce to the = 0 case). Since and are uncorrelated with the same mean and while , Lemma 1 promises that
So for any c between 0 and 1,
which then suggests that for such c, be estimated as
Finally, consider estimating . With the usual notation for averages of ’s and ,
So once more applying Lemma 1 (to the sample variance of uncorrelated variables with a common mean and ),
which in turn suggests the estimator
While our discussion has focused exclusively on moment results (and is thus not restricted to Gaussian models), there is much traditional interest and a huge literature concerned with distributional (and inference) results when one adds normality to the kind of assumptions we’ve made. Our reviewers have made several interesting points regarding connections to that literature. If one adds (joint) normality to the assumptions of Lemma 1, the resulting distribution for S2 is not chi-squared, but rather that of a weighted average of independent chi-square variables. On the other hand, under the normal one-way random effects model, our is sometimes referred to as the unweighted mean square, and pages 68-73 of Burdick and Graybill (1992) argue that suitably scaled, it is approximately chi-square. Further, this result has been used by El-Bassiouni and Abelhafez (2000) to produce valid confidence intervals for in this context. Finally, pages 98-106 of Burdick and Graybill argue that in the normal version of the two-factor nested design, provided c is suitably chosen, the quantity is approximately chi-square.
Financial support of the Deutsche Forschungsgemeinschaft (SFB 475, “Reduction of Complexity in Multivariate Data Structures”) through the University of Dortmund and of the Los Alamos National Laboratory Statistical Sciences Group is gratefully acknowledged by the first author.
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Stephen B. Vardeman
Departments of Statistics and Industrial and Manufacturing Systems Engineering
Iowa State University
Ames, IA 50011-1210
Joanne R. Wendelberger
Statistical Sciences Group
Los Alamos National Laboratory
Los Alamos, NM
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