Example 1: Swets et al 2008, in Memory and Cognition
The paper we consider first is:
Swets, B., Desmet, T., Clifton, C., & Ferreira, F. (2008). Underspecification of syntactic ambiguities: Evidence from self-paced reading. Memory & Cognition, 36(1), 201-216.
This paper is an influential and important one in psycholinguistics. It has been cited some 263 times according to google scholar. The central claim that the paper makes is that when a sentence has a globally ambiguous syntactic attachment, reading time (this is the self-paced reading method) is faster compared to unambiguous baseline conditions when the language comprehension task is superficial. When the comprehension task involves deep processing, this ambiguity advantage disappears. The experiment design is as follows:
There are three syntactic attachment types (a within subjects factor):
Ambiguous The maid of the princess who scratched herself in public was terribly humiliated.
N1 attachment The son of the princess who scratched himself in public was terribly humiliated.
N2 attachment The son of the princess who scratched herself in public was terribly humiliated.
The critical region where the interesting action happens is the post-critical region, the phrase in public following the reflexive (himself/herself).
There are three other levels of another, between-subject factor: question type (qtype). After reading each sentence, different subjects were shown either questions about the relative clause (RC questions–this is the deep processing condition), superficial questions, or were asked questions only occasionally.
Thus, this is a 3x3 factorial design, with one within-subjects factor (called attachment), and one between-subjects factor (called qtype).
We expect an interaction between the attachment and qtype factors. Let’s see how the evidence for this interaction was reported in the paper, and where things go wrong.
First, load the data:
## install from: https://github.com/bnicenboim/bcogsci as follows:
## # install.packages("devtools")
## devtools::install_github("bnicenboim/bcogsci")
library(bcogsci)
data("df_swets08")
The data frame for the post-critical region looks like this:
head(df_swets08)
## item subj resp.RT qtype attachment RT
## 41473 1 6 2089 RC questions N2 attachment 2379
## 41474 1 104 1831 occasional ambiguous 946
## 41475 1 94 2252 RC questions N1 attachment 1083
## 41476 1 150 4941 RC questions N1 attachment 1342
## 41477 1 132 6954 RC questions N1 attachment 1489
## 41478 1 103 472 occasional ambiguous 1400
The dependent measure is RT (reading time); resp.RT is the question response time. We will ignore the latter measure here.
A barplot shows the expected interaction pattern:
means<-round(with(df_swets08,tapply(RT,
IND=list(attachment,qtype),mean)))
barplot(means,beside=TRUE)
It does look like the qtype x ambiguity interaction will hold up–there seems to be a difference in the relative heights between the three barplots for qtype.
In preparation for a linear mixed models analysis, we set up orthogonal contrast coding (Helmert contrasts). The idea here is to compare the following groups of conditions:
- The ambiguous vs the unambiguous conditions (amb)
- The two unambiguous conditions (att)
- The deep vs the shallow questions types (depth)
- The two shallow question types (shallow)
## helmert coding for attachment:
df_swets08$ambig<-ifelse(df_swets08$attachment=="ambiguous",2,-1)
df_swets08$att<-ifelse(df_swets08$attachment=="N2 attachment",-1,
ifelse(df_swets08$attachment=="N1 attachment",1,
0))
## helmert coding for depth of processing:
df_swets08$depth<-ifelse(df_swets08$qtype=="RC questions",2,-1)
df_swets08$shallow<-ifelse(df_swets08$qtype=="occasional",-1,
ifelse(df_swets08$qtype=="superficial",1,0))
This gives us several new columns, which will be used to fit a linear mixed model:
head(df_swets08)
## item subj resp.RT qtype attachment RT ambig att depth shallow
## 41473 1 6 2089 RC questions N2 attachment 2379 -1 -1 2 0
## 41474 1 104 1831 occasional ambiguous 946 2 0 -1 -1
## 41475 1 94 2252 RC questions N1 attachment 1083 -1 1 2 0
## 41476 1 150 4941 RC questions N1 attachment 1342 -1 1 2 0
## 41477 1 132 6954 RC questions N1 attachment 1489 -1 1 2 0
## 41478 1 103 472 occasional ambiguous 1400 2 0 -1 -1
## sanity check: is the contrast coding correct?
xtabs(~attachment+ambig,df_swets08)
## ambig
## attachment -1 2
## ambiguous 0 1728
## N1 attachment 1728 0
## N2 attachment 1728 0
xtabs(~attachment+att,df_swets08)
## att
## attachment -1 0 1
## ambiguous 0 1728 0
## N1 attachment 0 0 1728
## N2 attachment 1728 0 0
xtabs(~qtype+depth,df_swets08)
## depth
## qtype -1 2
## occasional 1728 0
## RC questions 0 1728
## superficial 1728 0
xtabs(~qtype+shallow,df_swets08)
## shallow
## qtype -1 0 1
## occasional 1728 0 0
## RC questions 0 1728 0
## superficial 0 0 1728
We will use this coding below.
OK, now we are ready to go. First, the standard ANOVA analysis, then the LMM analysis.
Investigating the higher-order interaction using ANOVA vs LMMs
Next, we use a repeated measures ANOVA and then fit a linear mixed model, looking at main effects and interactions. First, we fit a model with raw reading times (this obviously the wrong thing to do, but that’s the dependent measure used in the published paper).
ANOVA analysis for the higher order interaction
bysubjdf_swets08<-aggregate(RT~subj+attachment +
qtype,mean,data=df_swets08)
library(rstatix)
##
## Attaching package: 'rstatix'
## The following object is masked from 'package:stats':
##
## filter
res_anova<-anova_test(data = bysubjdf_swets08,
dv = RT,
wid = subj,
between = qtype,
within = attachment
)
get_anova_table(res_anova)
## ANOVA Table (type II tests)
##
## Effect DFn DFd F p p<.05 ges
## 1 qtype 2.00 141.00 5.290 0.006000 * 0.054
## 2 attachment 1.80 253.18 8.496 0.000458 * 0.014
## 3 qtype:attachment 3.59 253.18 2.972 0.024000 * 0.010
This looks great; we have the expected interaction. But if we log-transform the aggregated data, the interaction is gone!!!
bysubjdf_swets08$logrt<-log(bysubjdf_swets08$RT)
res_anovalog<-anova_test(data = bysubjdf_swets08,
dv = logrt,
wid = subj,
between = qtype,
within = attachment
)
get_anova_table(res_anovalog)
## ANOVA Table (type II tests)
##
## Effect DFn DFd F p p<.05 ges
## 1 qtype 2 141 5.163 7.00e-03 * 0.057
## 2 attachment 2 282 10.158 5.49e-05 * 0.013
## 3 qtype:attachment 4 282 2.148 7.50e-02 0.005
The effect disappears because the significant interaction is due to a few extreme values, which the log transform down-weights.
This is really bad news, because it means that there is really no evidence in this paper for an ambiguity advantage.
Now, if you are a psychologist, you are probably feeling outraged: “Hey, cognition happens on the millisecond scale!!! You cannot log-transform the data!”. To which I would respond: (a) the Normal likelihood model you assume will predict negative reading times; are you OK with that prediction?, and (b) try explaining your logic to a real statistician (good luck, you will need it). For me, it’s amusing to watch people hold forth confidently on the importance of not log-transforming reading time data.
Linear mixed models analysis for the higher order interaction
Next, we fit a linear mixed model. For the Swets et al claim to hold up, there would have to be an interaction between ambig (whether the RC attachment is ambiguous or not) and depth (whether the question type was deep or not).
There is no such interaction, even when one fits the simplest linear mixed models of all (varying intercepts only).
library(lme4)
## Loading required package: Matrix
m1<-lmer(RT ~ (ambig+att)*(depth + shallow) + (1|subj)+
(1|item),df_swets08)
## the above is equivalent to:
m1<-lmer(RT~ambig+depth + ambig:depth +att:depth + shallow+ ambig:shallow + att:shallow + (1|subj)+
(1|item),df_swets08)
m1NULL<-lmer(RT~ambig+depth + #ambig:depth
att:depth + shallow+ ambig:shallow + att:shallow + (1|subj)+
(1|item),df_swets08)
anova(m1,m1NULL)
## refitting model(s) with ML (instead of REML)
## Data: df_swets08
## Models:
## m1NULL: RT ~ ambig + depth + att:depth + shallow + ambig:shallow + att:shallow + (1 | subj) + (1 | item)
## m1: RT ~ ambig + depth + ambig:depth + att:depth + shallow + ambig:shallow + att:shallow + (1 | subj) + (1 | item)
## npar AIC BIC logLik deviance Chisq Df Pr(>Chisq)
## m1NULL 10 81342 81408 -40661 81322
## m1 11 81344 81416 -40661 81322 0.2263 1 0.6343
There is a better analysis, on the log scale, but there is still no evidence for an interaction. I skip that analysis here.
So, even with a raw RT analysis, there is no evidence for a ambiguity:depth interaction in these data. This is what usually happens to me when I analyze published data; I can only rarely get to the same conclusion as in the published data.
But this was just a sanity check, let’s get to the subset analysis next. That’s the main issue I want to discuss here.
Subset analyses
The next thing to look at is whether there an effect of ambiguity nested within the question types: within RC questions vs the non-RC questions, is there an effect of ambiguity?
In the paper, the authors make the following claims:
- “…in the superficial question conditions, participants read ambiguous sentences faster than disambiguated sentences, and no reading time differences were observed for N1 versus N2 disambiguation.”
For this we needed a nested contrast coding: Within RC questions, the effect of ambiguity and attachment, and within the other question types, the effect of ambiguity and attachment.
Question type: RC RC RC Super Super Super Occ Occ Occ
Sentence type: A N1 N2 A N1 N2 A N1 N2
RCambig 2 -1 -1 0 0 0 0 0 0
RCatt 0 1 -1 0 0 0 0 0 0
Sambig 0 0 0 2 1 -1 0 0 0
Satt 0 0 0 0 1 -1 0 0 0
Oambig 0 0 0 0 0 0 2 -1 1
Oatt 0 0 0 0 0 0 0 1 -1
RC 2 2 2 -1 -1 -1 -1 -1 -1
NonRC 0 0 0 1 1 1 -1 -1 -1
Here, we have three pairs of nested comparison, for each of the three question types (RC (relative clause questions), O(ccasional), S(uperficial)): the ambiguity effects (the ambiguous condition vs the mean of N1/N2 attachment), and the N1 vs. N2 attachment effect. The contrast RC refers to the effect of the question type RC questions with the average of the other two question types; and NonRC compares the superficial and occasional question type conditions/
Here is the nested coding:
df_swets08$RCambig<-ifelse(df_swets08$qtype=="RC questions" & df_swets08$attachment=="ambiguous", 2,
ifelse(df_swets08$qtype=="RC questions" &
df_swets08$attachment!="ambiguous", -1,0))
df_swets08$RCatt<-ifelse(df_swets08$qtype=="RC questions" & df_swets08$attachment=="N1 attachment", 1,ifelse(df_swets08$qtype=="RC questions" &
df_swets08$attachment=="N1 attachment", -1,0))
df_swets08$Sambig<-ifelse(df_swets08$qtype=="superficial" & df_swets08$attachment=="ambiguous", 2,
ifelse(df_swets08$qtype=="superficial" &
df_swets08$attachment!="ambiguous", -1,0))
df_swets08$Satt<-ifelse(df_swets08$qtype=="superficial" &
df_swets08$attachment=="N1 attachment", 1,ifelse(df_swets08$qtype=="superficial" &
df_swets08$attachment=="N1 attachment", -1,0))
df_swets08$Oambig<-ifelse(df_swets08$qtype=="occasional" & df_swets08$attachment=="ambiguous", 2,
ifelse(df_swets08$qtype=="occasional" &
df_swets08$attachment!="ambiguous", -1,0))
df_swets08$Oatt<-ifelse(df_swets08$qtype=="occasional" & df_swets08$attachment=="N1 attachment", 1,ifelse(df_swets08$qtype=="occasional" &
df_swets08$attachment=="N1 attachment", -1,0))
df_swets08$RC<-ifelse(df_swets08$qtype=="RC questions",2,-1)
df_swets08$NonRC<-ifelse(df_swets08$qtype=="superficial",1,
ifelse(df_swets08$qtype=="occasional",-1,0))
ANOVA analysis (incorrect)
The way Swets et al analyzed the data was by subsetting the data to the superficial-questions condition. But this approach drastically changes the amount of data available for computing the most important variance component: the standard deviation estimate of the residuals. The aggregation is also wiping out by item variance (although the authors did do a by item analysis, that’s still not good enough as we need both variance components–by subject and by item–in the model simultaneously, otherwise we will underestimate the variance).
superficial<-subset(df_swets08,qtype="superficial")
bysubjsup<-aggregate(RT~subj+attachment,mean,
data=superficial)
res_anovasup<-anova_test(data = bysubjsup,
dv = RT,
wid = subj,
within = attachment
)
get_anova_table(res_anovasup)
## ANOVA Table (type III tests)
##
## Effect DFn DFd F p p<.05 ges
## 1 attachment 1.77 253.04 8.268 0.000595 * 0.013
Here, we get a significant effect of attachment in the superficial conditions. Looks good, right? Wrong.
Analysis using LMMs: subsetted vs full data comparison
Here is the analysis with the full data using nested coding. I fit the most complex model that converged.
m_nested<-lmer(RT~RCambig+RCatt+Sambig+Satt+Oambig+Oatt+
RC+NonRC+(1+RCambig+RCatt||subj)+
(1+RCambig+RCatt||item),df_swets08)
#summary(m_nested)
## ANOVA test on the overall effect of ambiguity in Superficial:
m_nestedNULL<-lmer(RT~RCambig+RCatt+Satt+Oambig+Oatt+
RC+NonRC+(1+RCambig+RCatt||subj)+
(1+RCambig+RCatt||item),df_swets08)
anova(m_nested,m_nestedNULL)
## refitting model(s) with ML (instead of REML)
## Data: df_swets08
## Models:
## m_nestedNULL: RT ~ RCambig + RCatt + Satt + Oambig + Oatt + RC + NonRC + ((1 | subj) + (0 + RCambig | subj) + (0 + RCatt | subj)) + ((1 | item) + (0 + RCambig | item) + (0 + RCatt | item))
## m_nested: RT ~ RCambig + RCatt + Sambig + Satt + Oambig + Oatt + RC + NonRC + ((1 | subj) + (0 + RCambig | subj) + (0 + RCatt | subj)) + ((1 | item) + (0 + RCambig | item) + (0 + RCatt | item))
## npar AIC BIC logLik deviance Chisq Df Pr(>Chisq)
## m_nestedNULL 15 81305 81404 -40638 81275
## m_nested 16 81305 81410 -40636 81273 2.5734 1 0.1087
We get a p-value of 0.11!! The effect of ambiguity within superficial conditions is no longer significant!!
Now, suppose we had subset the data to superficial questions only. Let’s redo the above analysis, but subsetting the data:
m_nestedsubset<-lmer(RT~Sambig+Satt+(1|subj)+
(1|item),subset(df_swets08,qtype=="superficial"))
## ANOVA test on the overall effect of ambiguity in Superficial:
m_nestedsubsetNULL<-lmer(RT~Satt +(1|subj)+
(1|item),subset(df_swets08,qtype=="superficial"))
anova(m_nestedsubset,m_nestedsubsetNULL)
## refitting model(s) with ML (instead of REML)
## Data: subset(df_swets08, qtype == "superficial")
## Models:
## m_nestedsubsetNULL: RT ~ Satt + (1 | subj) + (1 | item)
## m_nestedsubset: RT ~ Sambig + Satt + (1 | subj) + (1 | item)
## npar AIC BIC logLik deviance Chisq Df Pr(>Chisq)
## m_nestedsubsetNULL 5 25827 25854 -12908 25817
## m_nestedsubset 6 25823 25856 -12906 25811 5.4424 1 0.01965 *
## ---
## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
When we subset the data the way Swets et al did, now we get a significant p-value of 0.01!!
