For reading up on some basics, see ANOVA - What Is It?.

A car brand had 18 respondents rate 3 different car ads on attractiveness. The resulting data -part of which are shown above- are in adratings.sav. Some background variables were measured as well, including the respondent’s gender. The question we'll try to answer is:
are the 3 ads rated equally attractive and does gender play any role here?
Since we'll compare the means of 3(+) variables *measured on the same respondents*, we'll run a repeated measures ANOVA on our data. We'll first overview a simple but solid approach for the entire process. We'll then explain the what and why of each of these steps as we'll carry out the analysis step-by-step.

## Factorial ANOVA - Basic Workflow

## Data Inspection

First, we're not going to analyze any variables if we don't have a clue what's in them. The very least we'll do is inspect some histograms for outliers, missing values or weird patterns. For gender, a bar chart would be more appropriate but the histogram will do.

## SPSS Basic Histogram Syntax

***Quick check for abnormal distributions / outliers / missing values.**

frequencies gender ad1 to ad3/format notable/histogram.

You can now verify for yourself that **all distributions look plausible** and there's no missing values or other issues with these variables.

## Assumptions for Repeated Measures ANOVA

- Independent and identically distributed variables (“
**independent observations**”). **Normality**: the test variables follow a multivariate normal distribution in the population.**Sphericity**: the variances of*all difference scores*among the test variables must be equal in the population.^{1, 2, 3}

First, since each case (row of data cells) in SPSS holds a different person, the **observations are probably independent**.

Regarding the **normality** assumption, our previous histograms showed some skewness but nothing too alarming.

Last, Mauchly’s test for the **sphericity** assumption will be included in the output so we'll see if that holds in a minute.

## Running Repeated Measures ANOVA in SPSS

We'll first run a very basic analysis by following the screenshots below. The initial results will then suggest how to nicely fine tune our analysis in a second run.

show license.

may be absent from your menu if you don't have the SPSS option “Advanced statistics” installed. You can verify this by runningThe within-subjects factor is whatever distinguishes the three variables we'll compare. We recommend you choose a meaningful name for it.

Select and move the three adratings variables in one go to the within-subjects variables box. Move gender into the between-subjects factor box.

These profile plots will nicely visualize our 6 means (3 ads for 2 genders) in a multiple line chart.

For now, we'll only tick

and in the subdialog. Clicking in the main dialog results in the syntax below.## SPSS Basic Repeated Measures ANOVA Syntax

***Basic repeated measures ANOVA with within and between subjects factor.**

GLM ad1 ad2 ad3 BY gender

/WSFACTOR=adtype 3 Polynomial

/MEASURE=attractiveness

/METHOD=SSTYPE(3)

/PLOT=PROFILE(adtype*gender)

/PRINT=DESCRIPTIVE ETASQ

/CRITERIA=ALPHA(.05)

/WSDESIGN=adtype

/DESIGN=gender.

## Output - Select and Reorder

Since we're not going to inspect all of our output, we'll first delete some items as shown below.

Next, we'll move our profile plots up by dragging and dropping it right underneath the descriptive statistics table.

## Output - Means Plot and Descriptives

At the very core of our output, we just have **6 means**: 3 ads for men and women separately. Both men and women rate adtype 1 (“family car”, as seen in the variable labels) most attractive. Adtype 2 (“youngster car”) is rated worst and adtype 3 is in between.Technical note: these means may differ from DESCRIPTIVES output because the repeated measures procedure excludes all cases with one or more missing values from the entire procedure.

These means are nicely visualized in our profile plot.The “estimated marginal means” are equal to the observed means for the saturated model (all possible effects included). By default, SPSS always tests the saturated model for any factorial ANOVA. Now, what's really important is that the lines are far from parallel. This suggests an **interaction effect**: the **effect of adtype is different for men and women**.

Roughly, the line is almost horizontal for men: the three ads are rated quite similarly. For women, however, there's a huge difference between ad1 and ad2.

Keep in mind, however, that this is just a sample. Are the differences we see large enough for concluding anything about the **entire population** from which our sample was drawn? The answer is a clear “yes!” as we'll see in a minute.

## Output - Mauchly’s Test

As we mentioned under assumptions, repeated measures ANOVA requires sphericity and Mauchly’s test evaluates if this holds. The p-value (denoted by “Sig.”) is 0.264. We usually state that sphericity is met if p > 0.05, so the **sphericity assumption is met** by our data. We don't need any correction such as Greenhouse-Geisser of Huynh-Feldt. The flowchart below suggests which results to report if sphericity does (not) hold.

## Output - Within-Subjects Effects

First, the **interaction effect** between gender and adtype has a p-value (“Sig.”) of 0.017. If p < 0.05, we usually label an effect “statistically significant” so we have an interaction effect indeed as suggested by our profile plot.

This plot shows that the effects for adtype are clearly different for men and women. So we should test the effects of adtype for **male and female respondents separately**. These are called **simple effects** as shown in our flowchart.

There is a strong **main effect** for adtype: F(2,32) = 11.27, p = 0.000 too. But as suggested by our flowchart, we'll **ignore it**. The main effect lumps together men and women, which is justifiable only if these show similar effects for adtype. That is: if the lines in our profile plot would run roughly parallel but that's not the case here.

In other words, there's **no such thing as the effect** of adtype as a main effect suggests. The separate effects of adtype for men and women would be obscured by taking them together so we'll analyze them separately (simple effects) instead.

## Repeated Measures ANOVA - Simple Effects

There's no such thing as “simple effects” in SPSS’ menu. However, we can easily analyze male and female respondents separately with SPLIT FILE by running the syntax below.

***For simple effects: first split file by gender.**

sort cases by gender.

split file by gender.

## Repeated Measures ANOVA - Second Run

The SPLIT FILE we just allows us to analyze simple effects: repeated measures ANOVA **output for men and women separately**. We can either rerun the analysis from the main menu or use the dialog recall button as a handy shortcut.

We remove gender from the between-subjects factor box. Because the analysis is run for men and women separately, gender will be a constant in both groups.

As suggested by our flowchart, we'll now add some **post hoc tests**. Post hoc tests for within-subjects factors (adtype in our case) are well hidden behind the rather than the button. The latter only allows post hoc tests for between-subjects effects, which we no longer have.

## Repeated Measures ANOVA - Simple Effects Syntax

GLM ad1 ad2 ad3

/WSFACTOR=adtype 3 Polynomial

/MEASURE=attractiveness

/METHOD=SSTYPE(3)

/EMMEANS=TABLES(adtype) COMPARE ADJ(BONFERRONI)

/PRINT=DESCRIPTIVE ETASQ

/CRITERIA=ALPHA(.05)

/WSDESIGN=adtype.

## Simple Effects - Output

We interpret most output as previously discussed. Note that adtype has an effect for **female respondents: F(2,16) = 11.68, p = 0.001**. The precise meaning of this is that if *all three* population mean ratings would be equal, we would have a 0.001 (or 0.1%) chance of finding the mean differences we observe in our sample.

For males, this effect is not statistically significant: F(2,16) = 1.08, p = .362: if the 3 population means are really equal, we have a 36% chance of finding our sample differences; what we see in our sample does not negate our null hypothesis.

## Output - Post Hoc Tests

Right, we just concluded that adtype is related to rating for female but not male respondents. We'll therefore interpret the post hoc results for **female respondents only** and ignore those for male respondents.

But why run post hoc tests in the first place? Well, we concluded that the **null hypothesis of all population mean rating equal is not tenable**. However, with 3 or more means, we don't know exactly *which* means are different. A post hoc (Latin for “after that”) test -as suggested by our flowchart- will tell us just that.

With 3 means, we've 3 comparisons and each of them is listed twice in this table; 1 versus 3 is obviously the same as 3 versus 1. We quickly see that **ad1 differs from ad2 and ad3**. The difference between ad2 and ad3, however, is not statistically significant. Unfortunately, SPSS doesn't provide the t-values and degrees of freedom needed for reporting these results.

An alternative way to obtain these is running paired samples t-tests on all pairs of variables. The Bonferroni correction means that we'll multiply all p-values by the number of tests we're running (3 in this case). Doing so is left as an exercise to the reader.

Thanks for reading!

## References

- Field, A. (2013).
*Discovering Statistics with IBM SPSS*Newbury Park, CA: Sage. - Howell, D.C. (2002).
*Statistical Methods for Psychology*(5th ed.). Pacific Grove CA: Duxbury. - Wijnen, K., Janssens, W., De Pelsmacker, P. & Van Kenhove, P. (2002).
*Marktonderzoek met SPSS: statistische verwerking en interpretatie [Market Research with SPSS: statistical processing and interpretation].*Leuven: Garant Uitgevers.

## THIS TUTORIAL HAS 28 COMMENTS:

## By Jon K Peck on November 27th, 2016

Nice tutorial. One comment.

The pairwise comparisons in the example use the Bonferroni multiple-test correction (which is not the default in the dialog box). While widely used, Bonferroni can be overly conservative, but LSD and Sidak, the other choices, don't necessarily control the familywise error rate. However, using one of those, the STATS PADJUST extension command can apply other multiple-testing corrections to the test significance levels. With a small number of tests, this makes little difference, but it might matter with larger numbers.

## By Ruben Geert van den Berg on November 27th, 2016

Thanks for your feedback Jon!

I didn't want to go into too much detail because overly lengthy tutorials tend to scare people away ("too long to read"). So I simply followed David Howell who states that "[Bonferroni] does a good job of controlling the familywise error rate. [...] Generally compared well against Tukey's test in terms of power." (p. 493).

I do see the point with with larger numbers of tests. If sample sizes are huge and all p-values < 0.000, power won't be much of a concern but repeated measures designs typically don't have such large sample sizes. Do you have any

references on the performanceof the tests in the STATS PADJUST extension?## By Jon Peck on November 27th, 2016

STATS PADJUST is based on the R p.adjust function. From that doc below. Note the comment about Bonferroni.

The adjustment methods include the Bonferroni correction ("bonferroni") in which the p-values are multiplied by the number of comparisons. Less conservative corrections are also included by Holm (1979) ("holm"), Hochberg (1988) ("hochberg"), Hommel (1988) ("hommel"), Benjamini & Hochberg (1995) ("BH" or its alias "fdr"), and Benjamini & Yekutieli (2001) ("BY"), respectively. A pass-through option ("none") is also included. The set of methods are contained in the p.adjust.methods vector for the benefit of methods that need to have the method as an option and pass it on to p.adjust.

The first four methods are designed to give strong control of the family-wise error rate. There seems no reason to use the unmodified Bonferroni correction because it is dominated by Holm's method, which is also valid under arbitrary assumptions.

Hochberg's and Hommel's methods are valid when the hypothesis tests are independent or when they are non-negatively associated (Sarkar, 1998; Sarkar and Chang, 1997). Hommel's method is more powerful than Hochberg's, but the difference is usually small and the Hochberg p-values are faster to compute.

The "BH" (aka "fdr") and "BY" method of Benjamini, Hochberg, and Yekutieli control the false discovery rate, the expected proportion of false discoveries amongst the rejected hypotheses. The false discovery rate is a less stringent condition than the family-wise error rate, so these methods are more powerful than the others.

Note that you can set n larger than length(p) which means the unobserved p-values are assumed to be greater than all the observed p for "bonferroni" and "holm" methods and equal to 1 for the other methods.

Benjamini, Y., and Hochberg, Y. (1995). Controlling the false discovery rate: a practical and powerful approach to multiple testing. Journal of the Royal Statistical Society Series B 57, 289–300.

Benjamini, Y., and Yekutieli, D. (2001). The control of the false discovery rate in multiple testing under dependency. Annals of Statistics 29, 1165–1188.

Holm, S. (1979). A simple sequentially rejective multiple test procedure. Scandinavian Journal of Statistics 6, 65–70.

Hommel, G. (1988). A stagewise rejective multiple test procedure based on a modified Bonferroni test. Biometrika 75, 383–386.

Hochberg, Y. (1988). A sharper Bonferroni procedure for multiple tests of significance. Biometrika 75, 800–803.

Shaffer, J. P. (1995). Multiple hypothesis testing. Annual Review of Psychology 46, 561–576. (An excellent review of the area.)

Sarkar, S. (1998). Some probability inequalities for ordered MTP2 random variables: a proof of Simes conjecture. Annals of Statistics 26, 494–504.

Sarkar, S., and Chang, C. K. (1997). Simes' method for multiple hypothesis testing with positively dependent test statistics. Journal of the American Statistical Association 92, 1601–1608.

Wright, S. P. (1992). Adjusted P-values for simultaneous inference. Biometrics 48, 1005–1013. (Explains the adjusted P-value approach.)

## By Steve on July 28th, 2017

very nice tutorial. I got 2 questions. (1) If we add both gender and age groups into the between-subjects factors, and if they both have interaction to the ratings, do we re-run rmANOVA separately for their individual simple effects? (2) From your data file, I see there is education level, is it appropriate to put it as a covariate if we want to control for this variable. 1 more side question: can we put gender (a categorical variable) into covariate?

## By Eddington on October 30th, 2017

Thank you for the tutorial. It has been a great help. I am interested in the feedback you gave to questions posed by Steve on July 28th, 2017. If i have other questions i will get in touch.