Paul T. von Hippel
The Ohio State University
Journal of Statistics Education Volume 13, Number 2 (2005), www.amstat.org/publications/jse/v13n2/vonhippel.html
Copyright © 2005 by Paul T. von Hippel, 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: Asymmetry; Central tendency; Extreme values; Influence; Mean-median-mode inequality; Mode; Outliers; Robustness; Sensitivity
“In a skewed distribution, the mean is farther out in the long tail than is the median.” (Moore and McCabe 2003, p. 43)
“For skewed distributions, the mean lies toward the direction of skew (the longer tail) relative to the median.” (Agresti and Finlay 1997, p. 50)
Five textbooks extend the rule to cover the mode as well.
“In a skewed distribution..., the mean is pulled in the direction of the extreme scores or tail (same as the direction of the skew), and the median is between the mean and the mode.” (Thorne and Giessen 2000, pp. 81-82)
“[T]he mode, median, and mean do not coincide in skewed distributions, although their relative positions remain constant - moving away from the `peak’ and toward the `tail,’ the order is always from mode, to median, to mean.” (Levin and Fox, 2003, p. 85; also Levin and Fox 2004, p. 56)
The relationship between skew and measures of center is often illustrated with an idealized graph like Figure 1.
Authors typically state this rule without qualification, and some, like Levin and Fox above, indicate that it “always” holds. In follow-up exercises, some authors ask in what direction the mean or skew would “usually” or “probably” lie, but almost no author indicates what unusual or improbable circumstances might change the picture. (Ritchey 2000 mentions bimodal distributions, but does not elaborate.)
In this paper, we demonstrate that violations are not at all unusual if the distribution is discrete. Continuous densities seem much better behaved, though continuous violations can also be found or constructed. We discuss the reasons for these violations, and propose ways that teachers can allow for violations while continuing to develop students' basic intuition.
Under these definitions, discrete distributions can easily break the rule. For example, in the General Social Survey, respondents are asked how many people older than 18 live in their household. Figure 2 gives the responses for 2002 (1996 was similar). The skew is clearly to the right, yet the mean is left of the median and mode.
The key feature of Figure 2 is that there are substantially more cases on one side of the median than on the other. This is typical of discrete violations. In Figure 2, 38% of the cases are left of the median, 49% coincide with the median, and 13% are right of the median. The mean, or center of gravity, sits in the heavier left tail, but the longer right tail determines the skew. The rightmost values affect the skew more than the mean, because extreme values are cubed in the skew formula.
Continuous variables are less likely to break the rule, because the median of a continuous density must divide the area in half. But continuous violations can occur. For example, the Early Childhood Longitudinal Study (Kindergarten cohort) administered reading tests to 14,455 first graders in the spring of 2000. The distribution of scores is given in Figure 3. The skew is slightly to the left, yet the mean is just right of the median, and the median is right of the primary mode.
The continuous violation in Figure 3 is milder than the discrete violation in Figure 2. But in one respect the violations are similar: both figures have greater area in one tail, but greater length in the other. In Figure 3, the long tail is to the left of the primary mode, and the heavy tail is to the right. In addition, Figure 3 is slightly bimodal; we will discuss bimodal and multimodal distributions in Section 2.2.
The question arises whether better results could be obtained using an alternative definition of skew. An obvious attempt is the old “Pearson” formula where m is the median (e.g., Knoke, Bornstedt, and Mee 2002, p. 53). The Pearson formula makes a tautology of the relationship between skew, median, and mean – but it also has the counterintuitive implication that Figure 2, despite its long right tail, has negative skew.
Under this definition, well-known discrete distributions often put the median on the “wrong” side of the mean. Figure 4 plots the mean, median, mode, and skew of the Poisson distribution as a function of the parameter (which is also the mean). All Poisson distributions have an infinite right tail and positive skew (equal to ) – yet for more than 30% of parameter values, for example = .75 (Figure 5), the mean is less than the median. Since the Poisson is the limiting distribution for the binomial and hypergeometric, it follows that those distributions can break the rule as well. Again, the main reason is that, in discrete distributions, the median can divide the distribution into unequal areas. In Figure 5, for example, 47% of the distribution is left of the median, but only 17% is right of the median; the remaining 35% coincides with the median.
Continuous violations are rarer, but do exist. Multimodal continuous densities, for example, can easily break the rule. If the modes are narrow enough, a multimodal density approximates a discrete distribution, and we have already seen that discrete violations are commonplace. To construct a multimodal violation, simply take a discrete violation (e.g., Figure 2 or Figure 5) and add random normal “noise” to each value of X. The noise makes the distribution continuous, but if the noise variance is small there will be little change to the mean, median, mode, or skew. A density constructed in this way can be severely multimodal; such craggy densities are unusual, but not unheard of. The emission spectrum of hydrogen is severely multimodal (Dyson and Williams 1997), and craggy densities approximate the small-N sampling distributions of many sample statistics (e.g., Cytel 2004). Extreme cragginess is not required to exchange the positions of median and mean; Figure 3, for example, is only mildly bimodal.
It is also worth noting that a multimodal density can put the mode simply anywhere in relation to the median and mean. To see this, in Figure 1 add a tall spike of density on the right, at say X = 4. If the spike is tall enough, it becomes the primary mode, but if the spike is narrow enough it leaves the mean, median and skew substantially unchanged. The result is a right-skewed density where the primary mode is right of the median and mean. This sounds artificial, but a similar method could be used to construct the empirical violation in Figure 3; start with a left-skewed density with a single mode at X = 64, then add a taller lump near X = 52. The result is a left-skewed density where the primary mode is left of the median and mean. Using a similar method, Dudewicz and Mishra (1988, p. 217) construct a right-skewed density where the primary mode is between the median and mean.
Unimodal continuous densities are more cooperative. Groeneveld and Meeden (1977) prove that the skew gives the relative positions of mean, median and mode for the F, beta, and gamma densities (the gamma includes the exponential and the chi-square). More generally, MacGillivray (1981) proves the relationship for a large class of continuous unimodal densities including the entire Pearson family.
Outside the Pearson family, however, the rule can fail. For example, Groeneveld (1986) points out violations in the Weibull density with shape parameter . Figure 6 plots the mean, median, mode, and skew of the Weibull density for in the interval (3.20, 3.60). Although the skew is consistently positive, the mean can be on either side of the median, and the median or mean can be on either side of the mode. Figure 7 plots the Weibull density with = 3.44; the skew is to the right, but the mean is left of the median, and the median is left of the mode. This violation is quite mild, however; the skew is nearly invisible, and the mean, median, and mode differ hardly at all.
A stronger though more contrived violation arises from juxtaposing the triangular and exponential densities. Generalizing from examples in Dharmadhikari and Joag-Dev (1988), let f be a continuous density function that is triangular to the left of the origin and exponential to the right:
The parameter p in the interval (0, 1) determines what proportion of the area is in the triangular region. Figure 8 plots the mean, median, mode, and skew as functions of p. For p < 0.755, the skew is positive, yet the mean can be on either side of the median, and the mean or median can be on either side of the mode. Figure 9 plots this density with p = 0.75; the skew is to the right, yet the mean is left of the median, and the median is left of the mode.
Figure 9 follows the pattern of Figure 2, Figure 3 and Figure 7, with greater area to one side of the mode, but greater length to the other. In Figure 9, the left side of the mode has greater area, but the right side is infinitely long.
Again, the question arises whether the rule could be guaranteed by an alternative definition of skew. The answer is yes; a small theoretical literature has developed a suitable definition based on comparing the weights of the left and and right tails at all possible distances from the median (Ageel 2000; Dharmadhikari and Joag-Dev 1983; Zwet 1979). This definition, however, does not always square with our intuitive sense of skew; it implies, for example, than none of the counterexamples in this paper has skew at all.
Notwithstanding these exceptions, the relationship between skew, median, and mean conveys useful intuition. It seems desirable to preserve or enhance this intuition, without giving students an inaccurate picture.
In a data analysis course, it is certainly possible to continue teaching the relationship between skew, median, and mean. The treatment, however, should be more qualified than it is in current textbooks.
Discrete violations provide a nice opportunity to refine students’ interpretation of the median. Most textbooks teach that half the area falls on each side of the median, but this is far from true in Figure 2 and Figure 5. In discrete distributions, significant area can coincide with the median, so that the areas to each side can be unequal and substantially less than one-half. Continuous densities lack this possibility, so their violations tend to be rarer and milder.
The distinction between discrete and continuous variables is useful here, but it can be hard to draw in practice. An inherently continuous variable can be made discrete if the recorded values are rounded. Conversely, a Poisson distribution with (say) = 10.75 is “nearly continuous,” yet despite mild right skew the mean is left of the median (see Figure 4). The convergence between discrete and continuous distributions is well worth discussing in an introductory course.
A similar approach could be taken in a mathematical statistics course. Because the relationship between skew and center is just a rule of thumb, it can be taught rather informally. Teachers with an affection for the topic may ask students to demonstrate the rule using, say, the F density, or demonstrate its violation using the Poisson or Weibull.
An alternative is to avoid teaching the rule entirely. Instead of relating skew directly to the mean, it may be preferable to subordinate the relationship under the broader heading of influential points. The basic idea is that extreme values influence all distributional moments; a few large values increase the first moment (mean), the second moment (variance), and the third moment (skew) (Groeneveld 1991). The third moment will be most affected since the extreme values are cubed. From this perspective, the relationship between skew and mean comes from a shared sensitivity to influential points. A focus on influential points connects naturally to sensitive and robust statistics, and paves the way for a discussion of influence in bivariate and multivariate settings.
Cytel Software Corporation (2004), “StatXact Example 3: FDA Animal Toxicology Data Yields Sky-Scraper Distribution for Stratified Trend Test,” Accessed 18 February 2004. Available at www.cytel.com/StatXact/example_03.asp
Dharmadhikari, S.W., and Joag-dev, K. (1983), “Mean, Median, Mode III,” Statistica Neerlandica, 33, 165-168.
____________ (1988), Unimodality, Convexity, and Applications, Boston: Academic Press.
Dudewicz, E.J., and Mishra, S.N. (1988), Modern Mathematical Statistics, New York: Wiley.
Dyson, J.E., and Williams, D.A. (1997), The Physics of the Interstellar Medium, Bristol, UK: Institute of Physics.
Groeneveld, R.A. (1986), “Skewness for the Weibull Family,” Statistica Neerlandica, 40, 135-140.
Groeneveld, R.A. (1991), “An Influence Function Approach to Describing the Skewness of a Distribution,” The American Statistician, 45, 97-102
Groeneveld, R.A., and Meeden, G. (1977), “The Mode, Median, and Mean Inequality,” The American Statistician 31(3), 120-121.
MacGillivray, H.L. (1981), “The Mean, Median, Mode Inequality and Skewness for a Class of Densities,” Australian Journal of Statistics, 23(2), 247-250.
Silverman, B.W. (1986), Density Estimation for Statistics and Data Analysis, London: Chapman and Hall.
Zwet, W.R. van (1979), “Mean, Median, Mode II,” Statistica Neerlandica, 33, 1-5.
Agresti, A., and Finlay, B. (1997), Statistical Methods for the Social Sciences, 3rd ed., Upper Saddle River, NJ: Prentice Hall.
Bartz, A.E. (1999), Basic Statistical Concepts, 4th ed., Upper Saddle River, NJ: Prentice Hall.
Frankfort-Nachmias, C., and Leon-Guerrerro. (2002), Social Statistics for a Diverse Society, 3rd ed., Thousand Oaks, CA: Pine Forge.
Freund, J.E. (2004), Modern Elementary Statistics, Upper Saddle River, NJ: Pearson Prentice Hall.
Gravetter, F.J., and Wallnau, L.B. (2000), Statistics for the Behavioral Sciences, 5th ed., Belmont, CA: Wadsworth.
Kendrick, J.R. (2005), Social Statistics: An Introduction Using SPSS for Windows, Boston: Pearson.
Knoke, D., Bohrnstedt, G.W., and Mee, A.P. (2002), Statistics for Social Data Analysis, 4th ed., Itasca, IL: Peacock.
Levin, J., and Fox, J.A. (2003), Elementary Statistics in Social Research, 9th ed., Boston: Allyn and Bacon.
Levin, J., and Fox, J.A. (2004), Elementary Statistics in Social Research: The Essentials, Boston: Allyn and Bacon.
Maxwell, N. (2004), Data Matters: Conceptual Statistics for a Random World, Emeryville, CA: Key College Publishing.
Moore, D.S. (2000), The Basic Practice of Statistics, 2nd ed., New York: Freeman.
Moore, D.S., and McCabe, G.P. (2003), Introduction to the Practice of Statistics, 4th ed., New York: Freeman.
Ritchey, F. (2000), The Statistical Imagination: Elementary Statistics for the Social Sciences, Boston: McGraw-Hill.
Thorne, B.M., and Giessen, J.M. (2000), Statistics for the Behavioral Sciences, 3rd ed., Mountain View, CA: Mayfield.
4 textbooks that do not teach the relationship
Aron, A., and Aron, E.N. (2002), Statistics for the Behavioral and Social Sciences: A Brief Course, 2nd ed., Upper Saddle River, NJ: Prentice Hall.
Berry, D.A. (1996), Statistics: a Bayesian Perspective, Belmont, CA: Wadsworth.
Sweet, S.A., and Grace-Martin, K. (19xx), Data Analysis with SPSS: A First Course in Applied Statistics, 2nd ed., Boston: Allyn and Bacon.
Watkins, A.E., Scheaffer, R.L., Cobb, G.W. (2004), Statistics in Action: Understanding a World of Data, Emeryville, CA: Key College Publishing.
Volume 13, Number 3, of the Journal of Statistics Education contains a Letter to the Editor concerning this article.
Paul T. von Hippel
Department of Sociology and Initiative in Population Research
300 Bricker Hall
190 N. Oval Mall
The Ohio State University
Columbus, OH 43210
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