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Neuroscience 262 (2014) 92–106
CONCURRENT WORKING MEMORY TASK DECREASES THE STROOPINTERFERENCE EFFECT AS INDEXED BY THE DECREASEDTHETA OSCILLATIONS
Y. ZHAO, a D. TANG, a L. HU, a L. ZHANG, a�
G. HITCHMAN, a L. WANG a AND A. CHEN a,b*
aKey Laboratory of Cognition and Personality of Ministry of
Education, Faculty of Psychology, Southwest University,
Chongqing 400715, People’s Republic of China
bResearch Center of Psychological Development and Education,
Liaoning Normal University, Dalian, Liaoning 116029, People’s
Republic of China
Abstract—Working memory (WM) tasks may increase or
decrease the interference effect of concurrently performed
cognitive control tasks. However, the neural oscillatory
correlates of this modulation effect of WM on the Stroop task
are still largely unknown. In the present study, behavioral
and electroencephalographic (EEG) data were recorded from
32 healthy participants during their performance of the
single Stroop task and the same task with a concurrent WM
task. We observed that the Stroop interference effect repre-
sented in both response times (RTs) and theta-band event-
related spectral perturbation (ERSP) magnitude reduced
under the dual-task condition compared with the single-task
condition. The reduction of interference in theta-band ERSP
was further positively correlated with interference reduction
in RTs, and was mainly explained by the source in the left
middle frontal gyrus. In conclusion, the present study
suggests that the effect of concurrent WM tasks on the
reduction of the Stroop interference effect can be indexed
by EEG oscillations in theta-band rhythm in the centro-
frontal regions and this modulation was mediated by the
reduced cognitive control under the concurrent WM task.
� 2014 IBRO. Published by Elsevier Ltd. All rights reserved.
Key words: working memory load, Stroop interference effect,
EEG oscillations, theta-band rhythm.
0306-4522/13 $36.00 � 2014 IBRO. Published by Elsevier Ltd. All rights reservhttp://dx.doi.org/10.1016/j.neuroscience.2013.12.052
*Correspondence to: A. Chen, Faculty of Psychology, SouthwestUniversity, Chongqing 400715, People’s Republic of China. Tel:+86-23-68367642.
E-mail address: [email protected] (A. Chen).† Present address: NeuroImaging Center, Department of Neurosci-
ence, University Medical Center Groningen, University of Groningen,The Netherlands.Abbreviations: ACC, anterior cingulate cortex; ANOVA, analysis ofvariance; CWT, continuous Morlet wavelets transform; DI, dual &incongruent; DLPFC, dorsolateral prefrontal cortex; DN, dual & neutral;EEG, electroencephalography; ERD, event-related desynchronization;ERP, event-related potential; ERS, event-related synchronization;ERSP, event-related spectral perturbation; FDR, false discovery rate;ICA, independent component analysis; LORETA, low resolution brainelectromagnetic tomography; MRI, magnetic resonance imaging; RT,response time; SI, single & incongruent; SN, single & neutral; S-ROI,spatial regions of interest; TF-ROI, time-frequency regions of interest;WM, working memory.
92
INTRODUCTION
Cognitive control is a key function for human beings to
adapt flexibly and dynamically to the complex and ever-
changing environment. It represents the ability to select
a weaker, but task-relevant stimulus or behavior while
ignoring or inhibiting the stronger, but task-irrelevant one
(Miller and Cohen, 2001). WM refers to the ability of
temporary information storage and manipulation in the
brain (D’Esposito et al., 1995; Durstewitz et al., 2000).
While different, a huge body of evidence has convinced
researchers that the two constructs are to some degree
overlapped (D’Esposito et al., 1995; Miller, 2000; Kane
and Engle, 2002; Heitz and Engle, 2007; Salminen
et al., 2012; Unsworth et al., 2012; Barbey et al., 2013;
Morey and Bieler, 2013; Weldon et al., 2013). In
accordance with this notion, manipulating the type and/
or amount of WM load may significantly affect one’s
behaviors during performance of cognitive control tasks,
such as the Stroop task (Stroop, 1935), where
participants are instructed to make a response
according to the printed color of the word while ignoring
its semantic meaning. For example, de Fockert et al.
(2001) found a concurrent verbal WM task impaired the
performance of a name-face Stroop task, leading them
to conclude the WM task and cognitive control task
recruited the same limited central resources. Kim et al.
(2005) used several transformed versions of Stroop
tasks and found that when a verbal short-term WM task
was concurrently performed along with a meaning-
comparison Stroop task, in which participants had to
compare the meaning of a written colored word with the
color of a simultaneously presented patch, the Stroop
interference effect increased significantly. However, in
the second task, which used a similar paradigm,
participants had to identify whether the color of a patch
was the same as the color of a concurrently displayed
colored word. The word had meanings of ‘‘same’’ or
‘‘different’’. In that condition, the concurrent verbal short-
term WM task significantly boosted participants’
performance on the color-comparison Stroop task. Kim
et al. (2005) interpreted these results as suggesting that
in the meaning-comparison task, participants had to
process the meaning of written colored words; therefore,
word processing (the task target) in that condition
became a necessity. Consequently, concurrent verbal
WM took up the resource needed for target processing,
resulting in the Stroop interference effect increasing.
However, in the color-comparison Stroop task, the
processing of word meaning may have interfered with
ed.
participants’ decisions, thus words processing served as
the task distractor. As a result, concurrently loaded
verbal WM drained away the resource for words
processing, causing the interference effect of that
Stroop task to decrease.
Several subsequent studies to some extent replicated
Kim et al.’s results, finding concurrent WM tasks may
decrease Stroop interference (Park et al., 2007; Gil-
Gomez de Liano et al., 2010). Their observations, along
with Kim et al.’s original report, were generally
interpreted in terms of multiple resources theory (Navon
and Gopher, 1979; Egner et al., 2007; Egner, 2008).
That is, as the processing of the target and distractors
in a cognitive control task sometimes deploy different
resources, the interference effect will increase when the
concurrent WM task takes up the same resources as
the target processing, but decrease when the
concurrent WM task takes up the same resources as
the distractor processing (Kim et al., 2005; Park et al.,
2007; Zhao et al., 2010).
Although many studies have investigated the
modulation of concurrent WM tasks on the performance
of cognitive control tasks, the neural correlates of this
kind of modulation are still unknown. The few studies
investigating the related neural activities are limited to
functional magnetic resonance imaging (fMRI) or event-
related potential (ERP) studies (de Fockert et al., 2001;
Rissman et al., 2009; Spronk and Jonkman, 2012). To
the best of our knowledge, there have been no studies
exploring the neural oscillatory correlates in a cognitive
control task with concurrent WM demands. Due to their
advantages over the traditional ERP methods, EEG
oscillations have received a lot of recognition in recent
years for their use in cognitive neuroscience research
(Gevins et al., 1997; Klimesch, 1999; Raghavachari
et al., 2001; Hanslmayr et al., 2008; Lisman, 2010;
Cohen, 2011; Cohen and Cavanagh, 2011; Nigbur
et al., 2012; Tang et al., 2013). It has been known that
traditional ERP analysis performs well to detect scalp
electrophysiological activities time- and phase-locked to
the onset of a stimulus (e.g., presenting a visual
stimulus) or a response (e.g., pressing a response
button) (Cohen, 2011), which are usually termed evoked
activities. However, in addition to the well-known evoked
activities, there are also induced activities which are
time- but not phase-locked to the onset of a stimulus or
a response. These activities are believed to reflect
some kind of stimulus-induced ongoing EEG activity,
which carry important information about cognitive
processing but are usually averaged out as background
noises in the traditional ERP analysis (Makeig et al.,
2004). Some researchers have further stated that
induced activities reflect more complex brain features
that require iterative interactions between different
processing levels and memory, in comparison with
evoked activities, which have an instantaneous and
reflective feature (Eckhorn et al., 1990; Muller et al.,
1996). Thus, it is appealing to investigate the neural
correlates of higher brain functions such as concurrent
WM tasks on cognitive control with EEG methods.
The goal of the present research is to investigate the
neural correlates of a concurrent visual short-term WM
task on cognitive control with EEG methods. To achieve
this, we loaded the Chinese Stroop task with some to-
be-remembered meaningless visual shapes constructed
by hand-drawn lines (see Fig. 1), which were hard to be
associated with any meanings and could only be kept in
short-term WM by visual representations. The
concurrent visual short-term WM task may share a
common resource (for visual shape information
processing) with the Chinese characters based on the
findings that Chinese character recognition tends to be
strictly a visual form-to-meaning process, which is quite
different from English word recognition (Van Orden
et al., 1988; Plaut et al., 1996; Zhou and Marslen-
Wilson, 1996, 2000). The processing of color, on the
other hand, is believed to rely on another independent
cognitive processing system separated from shape
processing, in which only color information can be
stored and manipulated (Wheeler and Treisman, 2002;
Kim et al., 2005; Olsson and Poom, 2005). Thus we
speculated that the Chinese Stroop interference effect
under this type of concurrent short-term WM task may
decrease compared with the single Stroop task condition.
Previous studies have suggested that neural
oscillations in the theta band (4–7 Hz in frequency) and
alpha band (8–12 Hz in frequency) are often related to
higher level brain functions (Gevins et al., 1997;
Klimesch, 1999; Raghavachari et al., 2001; Hanslmayr
Fig. 1. Trial schema for the dual-task condition. The figure illustrates
a representative trial in the dual-task condition and its detailed timing.
The four WM load stimuli were randomly chosen for each trial from
the eight hand-drawn formations as depicted at the bottom right
corner of the picture. The Stroop stimulus in this trial as depicted in
this picture is a Chinese character meaning red but written in green.
(For interpretation of the references to color in this figure legend, the
reader is referred to the web version of this article.)
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 93
et al., 2008; Lisman, 2010; Cohen, 2011; Cohen and
Cavanagh, 2011; Nigbur et al., 2012; Tang et al., 2013).
For example, in early 2001, Jenson and Tesche found
theta power increased linearly with concurrent WM load
(Jensen and Tesche, 2002). Hanslmayr et al. (2008)
further used a Stroop task with EEG activities
simultaneously recorded, and found that compared with
congruent trials, incongruent trials were accompanied
with larger theta and frontal alpha activities, indicating
the activation of theta oscillations for the incongruent
condition reflected the activation of central executive
processes. On the other hand, frontal alpha activity is
also found to be related to WM and cognitive control
(Jensen et al., 2002; Hanslmayr et al., 2008;
Mathewson et al., 2011). Thus we speculated that
oscillations in the theta-band and/or alpha-band
frequency ranges may be the potential neural oscillatory
correlates for the modulation of concurrent WM task on
cognitive control.
EXPERIMENTAL PROCEDURES
Participants
Thirty-two right-handed participants (14 females) with
ages ranging from 18 to 26 (22.6 ± 2.1, mean ± SD)
took part in the present experiment. All participants
were free from neurological disease and psychoactive
medication use, had normal or corrected-to-normal
vision and normal color perception assessed by the
Ishihara Color Test. They all gave informed consent and
were paid for their participation. The Southwest
University’s local ethics committee approved the
procedure. In addition, the participants were unaware of
the purposes of the experiment.
Apparatus and stimuli
The experiment was conducted using an E-prime
software (Psychology Software Tools, Inc., Pittsburgh,
PA), running on a Dell computer. Stimuli were presented
on a 17-inch computer monitor with a refresh rate of
85 Hz. Participants were seated in a comfortable chair
in a dim, sound-attenuated chamber at a distance of
approximately 60 cm from the screen. They were
instructed to keep relaxed and to respond by pressing
one of the pre-specified keys on a standard computer
keyboard.
The Stroop task consisted of two different conditions:
neutral and incongruent. For the neutral condition, the
stimulus was a colored Chinese character randomly
selected from the set of three neutral Chinese
characters: ‘‘格,’’ ‘‘是,’’ or ‘‘法.’’ (‘‘grid’’, ‘‘yes’’ or ‘‘law’’)
which are familiar to all native speakers and whose
pronunciation, meaning and formation are all different
from the color characters. For the incongruent condition,
the stimulus was also a colored character randomly
chosen among four Chinese color names: ‘‘红,’’ ‘‘黄,’’
‘‘蓝,’’ or ‘‘绿’’ (‘‘red’’, ‘‘yellow’’, ‘‘blue’’, or ‘‘green’’). The
above characters were colored in red (RGB 255, 0, 0),
blue (RGB 0, 0, 255), yellow (RGB 255, 255, 0), or
green (RGB 0, 255, 0) accordingly. The printed color
and semantics of the character in the incongruent
condition were different (e.g. RED was colored in
green). The whole WM task stimulus repository
(including all the to-be remembered items used in our
experiment) consisted of eight different imitative
structures constructed by hand-drawn lines. These
structures are similar to the structures of Chinese
characters but are not associated with any meanings. In
each trial of the WM task, four different structures were
randomly chosen and ordered from the whole
repository. In addition, they were displayed along a
horizontal row at the center of the screen with equal
spacing between each structure. All stimuli were
displayed on a gray (RGB 128, 128, 128) background.
Experimental design
The experiment included two within-subjects factors: the
task and congruency. The task factor consisted of either
the single Stroop task condition or the dual-task
condition (maintaining a WM load while performing the
Stroop task). The congruency factor had two levels:
‘‘neutral’’ or ‘‘incongruent’’. Thus the two factors resulted
in four different conditions: single & neutral (SN), single
& incongruent (SI), dual & neutral (DN), and dual &
incongruent (DI), with each condition including 96 trials.
Procedure and task
In the dual-task condition (Fig. 1), each trial began with
four horizontally ordered structures displayed at the
center of the screen for 2000 ms. Participants were
instructed to remember and maintain all the four
structures during each trial by visual encoding and not to
try to associate the structures with any meaning. After
the structures disappeared, a fixation cross was
presented for 500 ms, followed by a blank screen for
300–500 ms (interval varied randomly). Then a color-
word Stroop stimulus appeared, for a maximum duration
of 2000 ms. Participants were instructed to respond to
the printed color of the character and ignore its meaning
by pressing the ‘‘D’’ key using the left middle finger if the
printed color of the character was red, the ‘‘F’’ key using
the left forefinger if the printed color of the character
was yellow, the ‘‘J’’ key using the right forefinger if the
printed color of the character was green, and the ‘‘K’’
key using the right middle finger if the printed color of
the character was blue. They were instructed to respond
as quickly and accurately as possible. After a response
was made, the Stroop stimulus screen immediately
disappeared and was followed by a 100-ms blank
screen. Then a fixation cross was presented for 500 ms,
which was followed by the memory test display. During
the memory test stage, one structure appeared at the
center of the screen, which was either taken from the
four to-be-memorized structures presented in the load
display at the beginning of this trial or from the
remaining unseen structures. Participants were asked to
press the ‘‘T’’ key using the left forefinger if the test
structure matched one of the structures in the to-be-
memorized set, or the ‘‘U’’ key using the right forefinger
if not. The memory test was displayed until a response
94 Y. Zhao et al. / Neuroscience 262 (2014) 92–106
was made. Lastly, a blank screen was presented for 500–
800 ms (interval varied randomly).
In the single Stroop task condition, a 2000-ms blank
screen (replacing the WM load screen) was presented
at the beginning of each trial. Then the task
configuration was similar to that of dual-task condition
following the display of the WM load screen. After the
response to the Stroop stimulus was made, a 500–
800 ms blank screen was presented for a randomly
varied duration. Then the next trial began.
The task conditions were performed in separated
blocks and in a successive manner. The order of the
two task conditions was counterbalanced between
participants. Each task contained two successive
blocks, each of which contained 96 trials (trial
sequences were randomized), thus resulting in 384 trials
in total. The numbers of all possible color-word
combinations were the same in each block, so was the
proportion of incongruent and neutral trials. In the dual-
task condition, the proportion of the correct ‘‘T’’ and ‘‘U’’
responses in the memory test period was equal.
Between blocks there was a two-minute break allowing
participants to rest. Prior to four experimental blocks,
participants accomplished a training block which only
included the neutral Stroop stimuli from the dual-task
condition. Only when accuracy in the training block
exceeded 80% could participants go on to perform the
formal experiment.
Electrophysiological recording and analysis
EEG data were collected using a 64-channel Brain
Products system (Brain Products, GmbH, Germany;
pass band: 0.01–100 Hz, sampling rate: 500 Hz) that
was connected to a standard EEG cap based on the
extended 10–20 system. The left mastoid was used as
the reference channel, and all channel impedances
were kept lower than 5 kX. The electro-oculographic
signals were simultaneously recorded from four surface
electrodes, which were placed over the higher and lower
eyelid and 1 cm lateral to the outer corner of the left and
right orbit to monitor ocular movements, and eye blinks.
EEG data were preprocessed using routines taken
from EEGLAB, an open source toolbox running in the
MATLAB environment for electrophysiological signal
processing (Delorme and Makeig, 2004). After being
imported into MATLAB, the continuous data were re-
referenced to the average of both mastoids. Four
electro-oculographic channels and one right mastoid
channel were rejected. We then removed the linear
trend from the continuous data with the MATLAB
function ‘detrend()’. After that, data were digitally filtered
with a low cutoff value of 1 Hz and a high cutoff value of
30 Hz, respectively, using a finite impulse response
filter. Subsequently, the resulting data were segmented
into a time window from �800 to 2500 ms that was
time-locked to the Stroop stimulus onset and baseline
corrected using the pre-stimulus interval (�800 ms to
0 ms). Such relatively long epochs were taken for the
following reasons: (1) subsequent independent
component analysis (ICA) performs better with more
data points (Jung et al., 1998) and (2) edge effects in
the time–frequency analysis caused by sudden
transitions from signal values between trials would not
influence signals in the window of interest (Cohen and
Cavanagh, 2011). Epochs contaminated by spurious
gross-movement and other non-stereotyped artifacts
were identified by visual inspection and rejected.
Furthermore, any epochs corresponding to error or
missing trials (trials without responses) in the Stroop
task or WM task were further excluded from analysis.
We subsequently downsampled segmented data sets
from the original sampling rate of 500 Hz to 250 Hz,
after which the data sets were subjected to an ICA
algorithm provided in EEGLAB (Jung et al., 2000). In all
data sets, independent components representing eye
movements or blinks were identified by visual inspection
and removed. On average, 1.5 components were
removed (range, 0–2) per participant. After independent
component removal, additional baseline correction was
performed using the pre-stimulus time interval (�800 ms
to 0 ms). We then equalized the number of epochs
included in the four different conditions (DI, DN, SI, and
SN) of every participant by setting the number of
epochs in the condition with the least number of epochs
as a criterion and randomly selecting the same
corresponding number of epochs among all the epochs
in the other three conditions, respectively. This
procedure avoided potential confounding due to different
signal–noise ratios caused by different numbers of
epochs in each condition.
After all EEG data were preprocessed, an estimate of
the oscillatory power as a function of time and frequency
(time–frequency representation) was obtained from
single-trial EEG epochs using the continuous Morlet
wavelet transform (CWT) conducted by Letswave
software (http://amouraux.webnode.com) (Mouraux and
Iannetti, 2008). The parameters of central frequency (x)and restriction (r) in CWT were 5 and 0.15 respectively,
and time–frequency representations were explored from
1 to 30 Hz in steps of 0.58 Hz. Single-trial time–
frequency representations were then averaged to obtain
the averaged time–frequency representations of every
participant under each condition. The resulting averaged
time–frequency representations were exported from
Letswave and imported into MATLAB for further detailed
analysis.
To analyze the power modulation of ongoing EEG
rhythms after Stroop stimuli onset, ERSP was calculated
for every time–frequency pixel in the time–frequency
representations. For each estimated frequency, ERSP
was displayed as an increase or decrease of oscillatory
power relative to the baseline interval (�600 ms to
�200 ms) according to the formula: ERt,f%= [At,f � Rf]/
Rf, where At,f was the signal power at a given time t andat a given frequency f, and Rf was the averaged signal
power of frequency f within the baseline interval
(Pfurtscheller and Lopes da Silva, 1999). After
transforming the original power values to ERSP in the
time–frequency representations, we performed an
exploratory data-driven analysis routine to identify all the
time–frequency regions of interest (TF-ROIs) which were
most likely significantly modulated by factors of task and
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 95
congruency or their interaction, and their corresponding
spatial regions of interest (S-ROIs). Before proceeding to
the specific details of such a routine, it is necessary to
point out that we only analyzed the time window of
1200 ms after stimuli onset, because participants tended
to finish their responses for both tasks within about
1000 ms after Stroop stimuli onset.
The exploratory data-driven analysis routine was
performed as follows:
(1) We first roughly identified several TF-ROIs with
maximal modulations related to the two experimen-
tal factors and their interaction, respectively. We
achieved this by calculating the time–frequency dif-
ference maps corresponding to the respective mod-
ulations of two factors and their interaction across
all the electrodes, and then the TF-ROIs, showing
the largest modulation of each effect from the differ-
ence maps, were identified.
(2) We calculated the mean of all the time–frequency
pixels included in a specific TF-ROI for each
electrode. For every TF-ROI, two-way repeated-
measures analysis of variances (ANOVAs) were
performed for each electrode and the resulting F
value for the specific effect corresponding to this
TF-ROI was extracted. Then all of the extracted Fvalues corresponding to the electrodes were plotted
as a scalp map. Based on the scalp regions show-
ing most pronounced F values, three S-ROIs which
were related to corresponding effects were identi-
fied: centro-frontal electrodes [(F1 + Fz + F2+
FC1 + FCz + FC2)/6, identified for both the main
effect of congruency and the interaction effect
between task and congruency]; right centro-
parietal electrodes [(FC4 + FC6 + C4+ C6+
CP4+ CP6)/6, identified for the main effect of task
type]; frontal electrodes [(F1 + Fz + F2 + AF3
+ AF4)/5, identified for the other main effect of task
type.
(3) Based on the defined S-ROIs, we firstly calculated
the magnitude difference between incongruent
and neutral conditions [expressed in ER% of
(DI + SI � DN � SN)] in the centro-frontal S-ROI
[(F1 + Fz + F2 + FC1+ FCz + FC2)/6] to evalu-
ate the potential congruency main effect; we secondly
calculated the magnitude difference between dual-
task and single-task conditions [expressed in ER%
of (DI + DN � SI � SN)] in the right centro-parietal
S-ROI [(FC4+ FC6+C4+C6+CP4+ CP6)/6]
and the frontal S-ROI [(F1 + Fz + F2+ AF3
+ AF4)/5] to evaluate the potential main effect of
task type; we lastly calculated the magnitude differ-
ence according to the formula (SI � SN) �(DI � DN) [expressed in ER% in the centro-frontal
S-ROI (F1 + Fz + F2+ FC1 + FCz + FC2)/6] to
evaluate the potential interaction effect.
(4) For each obtained time–frequency representation of
magnitude difference (for the main effects of con-
gruency and task type, and the interaction effect
respectively), we tested whether and when the
resulting magnitudes within the post-stimulus inter-
val were significantly different from those within
the pre-stimulus interval using a bootstrapping
method (Delorme and Makeig, 2004; Durka et al.,
2004). At each time–frequency point in the post-
stimulus interval, investigated populations and ref-
erence populations were collected from 32 partici-
pants. The null hypothesis was that there was no
mean difference between these two populations.
Then a pseudo-t statistic between the two popula-
tions was calculated, and we estimated the proba-
bility distribution of the pseudo-t statistic from the
reference population by drawing with replacement
two populations of the same size. The permutation
was executed 5000 times. The distribution of the
pseudo-t statistics from the reference population
and the bootstrap p value for the null hypothesis
were then generated.
(5) This procedure yielded time–frequency distribu-
tions, in which the brain responses within the post-
stimulus interval were significantly different from
the reference interval (Hu et al., 2012; Peng et al.,
2012). To address the problem of multiple compar-
isons, the significance level (p value) was corrected
using a false discovery rate (FDR) procedure
(Durka et al., 2004). In addition, to control for
false-positive observations (Maris and Oostenveld,
2007), significant TF-ROIs were defined based on
the criteria that (1) the included time–frequency pix-
els were significantly different from the pre-stimulus
intervals at p< .01; (2) they had to be composed of
more than 75 consecutive significant time points
(300 ms) (Hu et al., 2013); (3) Frequencies below
4 Hz (Delta-band) were not considered for oscilla-
tions at such an extremely low frequency band is
often subject to artifacts due to sweating, move-
ment and electrode drift (He and Raichle, 2009).
After TF-ROIs and S-ROIs were identified, we
calculated the mean magnitude within the TF-ROIs at
corresponding S-ROIs for each condition. The resulting
values were entered into a two-way repeated-measures
ANOVA with the factors of task and congruency. Only
TF-ROIs showing significant modulations of corresponding
effects are reported.
Source localization analysis
We identified a TF-ROI (4–7 Hz, 400–1000 ms) in which
the modulation of the Stroop effect by Task type
occurred (see ‘Results’). We applied low-resolution
electromagnetic tomography analysis (LORETA) to
determine the cortical sources of the TF-ROI (Pascual-
Marqui et al., 1994, 1999; Pascual-Marqui, 1999; Frei
et al., 2001). LORETA solves the ‘‘inverse problem’’ by
finding the smoothest of all solutions with no
assumptions about the number, location, or orientation
of the generators. It uses a three-shell spherical head
model registered to the digitized Montreal Neurological
Institute (MNI305) MRI template. The solution space
corresponds to cortical gray matter of 2394 voxels
sampled at 7-mm resolution.
96 Y. Zhao et al. / Neuroscience 262 (2014) 92–106
We considered LORETA solutions in two time
windows (�600 to �200 ms and 400–1000 ms) for
theta-band (4–7 Hz) and for the four respective
conditions. The resulting LORETA values were
averaged across the respective time window and the
specific frequency window (4–7 Hz). To correspond to
the event-related changes of EEG (ERSP), we
subtracted the averaged baseline LORETA values
(�600 to �200 ms) from the averaged LORETA values
of 400–1000 ms after stimulus. As our major focus was
the interaction effect of Stroop interference by Task
type, we applied the formula [(SI � SN) � (DI � DN)] to
LORETA values to obtain the final LORETA image. The
maximum voxels in the image were reported based on
their MNI coordinates and corresponding Brodmann
areas (BAs).
RESULTS
Behavioral data
Descriptive statistics for both RTs and error rates in the
Stroop task as a function of experimental factors are
shown in Table 1. Only trials on which the subjects were
correct on the WM load task were included in the
analysis of results for the Stroop task, and only trials on
which the subjects were correct on both the WM task
and the Stroop task were included in the analyses of the
Stroop task RTs. Trials were further excluded from
analyses when the Stroop task RTs deviated by 3 or
more SDs from an individual subject’s overall mean RT.
A two-way within-subjects repeated-measures ANOVA
was performed on error rates in the Stroop task as a
function of task type (dual, single) and congruency
(incongruent, neutral). The results revealed a marginally
significant main effect of congruency [F(1, 31) = 3.51,
p= .07, g2 = .10], with more errors in the incongruent
condition. However, the main effect of task type was not
significant [F(1, 31) = 1.01, p= .32, g2 = .03], and
there was no significant interaction between congruency
and task-type factors [F(1, 31) < 1].
For the Stroop task RTs, a two-way within-subjects
repeated-measures ANOVA was performed. Results
revealed a significant main effect of congruency,
[F(1, 31) = 68.95, p< .0001, g2 = .69], showing a classic
Stroop interference effect. The main effect of task was
also significant [F(1, 31) = 58.19, p< .0001, g2 = .65].
However, there was no significant interaction between
the congruency and task-type factors [F(1,31) < 1].
Although the interaction between the congruency and
task-type factors was not significant for RTs, the
interference effect was smaller in the dual-task condition
than that in the single-task condition (see Table 1). On
the considerations that previous studies had shown a
significant positive correlation between the interference
effect and general RTs (Yeung et al., 2004, 2011;
Yeung and Nieuwenhuis, 2009) and that general
slowing accounted for a large part of the enlarged
interference effect observed in adult aging (Salthouse,
1996), we speculated that the Stroop interference effect
may be confounded by a general RT-slowing in the
dual-task condition. If that was the case, when general
RTs were equalized between the two task types, the
estimation of the interaction effect between congruency
and task type should be more accurate than when not
equalized. Based on this, Stroop interference effects
were corrected as proportions of baseline RTs, that is,
(incongruent RT - neutral RT)/neutral RT, separately on
dual- and single-task conditions for each subject (Maylor
and Lavie, 1998). After this, a paired-samples t test
(2-tailed) was carried out for the general RT weighted
Stroop interference effects in the dual- and single-task
conditions. Results revealed the effect of task type on
Stroop interference was marginally significant [t(31)= 2.32, p= 0.06], with a tendency of a smaller
interference effect in the dual-task condition compared
with that in the single-task condition.
EEG data during the Stroop task
The main effect of task type. The modulation of the
main effect of task type (dual, single task) happened
mainly in both the right centro-parietal electrode regions
and frontal electrode regions. The grand-averaged time–
frequency representations of the four different conditions
(DI, DN, SI, and SN) and the difference time–frequency
representation between the dual- and single-task
conditions [(DI + DN) � (SI + SN)] in the right centro-
parietal and frontal electrode regions are illustrated in
Fig. 2A, B, respectively. For the right centro-parietal
electrode regions, a TF-ROI including theta- and alpha-
bands (4–13 Hz in frequency, 800–1100 ms in latency)
that showed the most pronounced task-related effect
was defined (in rectangles in Fig. 2B, p< .05, FDR
corrected). The scalp topographies of ERSP magnitudes
for the DI, DN, SI, and SN conditions and the difference
between the dual-task and single-task conditions
[(DI + DN) � (SI + SN)] within the defined TF-ROI
(4–13 Hz, 800–1100 ms) are illustrated in Fig. 2C. The
mean ERSP magnitudes within the defined TF-ROI for
the four conditions (DI, DN, SI, and SN) were entered
into a two-way within-subjects repeated-measures
ANOVA. The results revealed a significant main effect of
task type, [F(1, 31) = 29.74, p< .001, g2 = .49]. For
the frontal electrode regions, a TF-ROI in the beta band
(13–23 Hz, 400–700 ms) that showed the most
Table 1. Behavioral measures in the single task and dual taska,b
Task Stroop congruency
Incongruent Neutral Incongruent-neutral
Type M SD M SD M SD
Single task
RTs 869 156 805 140 64 51
%E 3 3 2 3 1 3
Dual task
RTs 988 129 928 113 60 50
%E 3 4 3 4 1 4
a Mean correct reaction times (ms) and error rates on the Stroop task as a
function of working memory load and Stroop congruency.b M= mean; E%= error rate, calculated as a percentage; SD= standard
deviation.
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 97
pronounced task-related effect was defined (in rectangles
in Fig. 2B, p< .05, FDR corrected). The scalp
topographies of ERSP magnitudes for the four
conditions (DI, DN, SI, and SN) and the difference
between the dual-task and single-task conditions
[(DI + DN) � (SI + SN)] within the defined TF-ROI
(13–23 Hz, 400–700ms) are illustrated in Fig. 2C. The mean
ERSP magnitudes within the defined TF-ROI of the DI,
DN, SI, and SN conditions were entered into a two-way
within-subject repeated-measures ANOVA. The results
also revealed a significant main effect [F(1, 31) = 16.56,
p< .001, g2 = .35].
The main effect of congruency. The modulation of the
main effect of congruency happened mainly in the centro-
frontal electrode regions. The grand-averaged time–
frequency representations of the four conditions (DI,
DN, SI, and SN) and the difference time–frequency
Fig. 2. The grand-averaged time–frequency representations of the four conditions within the respective defined S-ROIs and corresponding scalp
topographies of magnitudes of the four conditions within the respective defined TF-ROIs. Panel A depicts the grand-averaged time–frequency
representations of the four different conditions (DI, DN, SI, and SN) within the respective defined S-ROIs. Each row corresponds to one S-ROI
corresponding to the largest modulation of the specific effects. From top to bottom: the right centro-parietal electrodes [(FC4 + FC6+ C4+ C6
+ CP4+ CP6)/6] corresponding to the task effect’s modulation; frontal electrodes [(F1 + Fz + F2 + AF3 + AF4)/5] corresponding to the task
effect’s other modulation; centro-frontal electrodes [(F1 + Fz+ F2 + FC1+ FCz + FC2)/6] corresponding to the congruency effect’s modulation
and centro-frontal electrodes [(F1 + Fz + F2 + FC1+ FCz + FC2)/6] corresponding to the interaction effect’s modulation. X-axis, time (ms); Y-axis, frequency (Hz). Panel B depicts the grand-averaged time–frequency representations for the corresponding magnitude difference reflecting
different kinds of effects at different S-ROIs and the results of corresponding bootstrapping statistical analyses at the significant level of p< .01
(FDR corrected). The time–frequency pixels displaying a significant difference from the baseline are colored in black. White rectangles outline the
TF-ROIs corresponding to each specific effect. Panel C depicts the scalp topographies reflecting the ERSP magnitude distributions within the
corresponding TF-ROIs (expressed in ER%) and the difference scalp topographies reflecting the corresponding different kinds of experimental
effects. The time interval for each row of maps changes with the time interval defined by the respective time–frequency ROIs. That is to say, for Task
modulation 1 (the uppermost row), the time interval is 800–1100 ms; for Task modulation 2 (the second row), the time interval is 400–700 ms; for
congruency modulation (the third row), the time interval is 400–1100 ms; for interaction modulation (the last row), the time interval is 400–1000 ms.
White rectangles outline the S-ROIs which show the largest modulation of corresponding effects on the scalp.
98 Y. Zhao et al. / Neuroscience 262 (2014) 92–106
representation between the incongruent and neutral
conditions [(DI + SI) � (DN + SN)] in the centro-frontal
electrode regions are illustrated in Fig. 2A, B,
respectively. A TF-ROI covering theta- and alpha-bands
(5–12 Hz in frequency, 400–1100 ms in latency) that
showed the most pronounced Stroop interference effect
was defined (in rectangles in Fig. 2B, p< .05, FDR
corrected). The scalp topographies of ERSP magnitudes
for the four conditions (DI, DN, SI, and SN) and the
difference between the incongruent and neutral
conditions [(DI + SI) � (DN + SN)] within the defined
TF-ROI (5–12 Hz, 400–1100 ms) are illustrated in
Fig. 2C. Note that a significantly stronger theta- and
alpha-band ERS was observed for the incongruent type
than for neutral type, which resulted in a clear positive
ERSP magnitude for the difference between the
incongruent and the neutral types in the centro-frontal
electrode regions. The mean ERSP magnitudes
(expressed in ER%) within the defined TF-ROI for the
DI, DN, SI, and SN conditions were entered into a two-
way within-subjects repeated-measured ANOVA. The
results revealed a significant main effect of congruency
[F(1, 31) = 39.15, p< .001, g2 = .56].
The interaction effect of congruency by task type. The
modulation of the interaction effect of congruency by task
type happened mainly in the centro-frontal electrode
regions. The difference time–frequency representation
for the interaction effect [(SI � SN � (DI � DN)] in the
centro-frontal electrode regions are illustrated in Fig. 2A,
B. A TF-ROI in the theta band (4–7 Hz in frequency,
400–1000 ms in latency) that showed the most
pronounced interaction effect was defined (in rectangles
in Fig. 2B, p< .05, FDR corrected). The scalp
topographies of ERSP magnitudes for the DI, DN, SI,
and SN conditions and the difference scalp
topographies for the interaction effect [(DI + SI) � (DN
+ SN)] within the defined TF-ROI (4–7 Hz, 400–
1000 ms) are illustrated in Fig. 2C. Note that there was
a stronger theta-band ERS within the centro-frontal
electrode regions for the incongruent condition
compared with the neutral condition in the single-task
condition. However, the theta-band ERS difference
between the incongruent and neutral conditions
disappeared in the dual task. The mean ERSP
magnitudes within the defined TF-ROI for the DI, DN,
SI, and SN conditions were entered into a two-way
within-subject repeated-measures ANOVA. The results
revealed a significant interaction between congruency
and task type, [F(1, 31) = 9.33, p= .005, g2 = .23].
Post hoc tests revealed that for the single-task
condition, theta-band ERS was significantly higher in the
incongruent type than that in the neutral type
(p< .001). However, for the dual-task condition, there
was not a significant difference between the incongruent
and neutral types (p= .29, Fig. 3A).
The validity of the reduced interference in theta bandERSP in the dual-task condition. To validate that the
reduced interference in theta rhythm observed in the
dual-task condition was robust, we have listed theta band
ERSP (4–7 Hz) under each condition for all participants
in Table 2 (Michels et al., 2008). As can be seen from
Table 2, for theta rhythm ERSP, the Stroop interference
effect for the single-task condition was robust, with 27
out of 32 participants showing larger or equal ERSP
values in the incongruent condition. The interference
effect in the dual-task condition was mixed across
participants, with nearly half of the participants (14 out of
32) showing the opposite modulation effect compared
with rest of the participants. The interaction effect
between Stroop congruency and Task was robust, with
23 out of 32 participants showing that the interference
effect in the dual-task condition was smaller than in the
single-task condition. As a contrast, we have also listed
alpha band ERSP (8–12 Hz) under each condition for all
participants in Table 3. As can be seen from Table 3, for
alpha rhythm ERSP, the Stroop interference effect for
Fig. 3. The effect of task type and congruency on theta-band ERSP (expressed in ER%) and the correlation between the interaction effect of
congruency by WM load expressed in theta-band ERSP and behavioral RTs. Panel A depicts the mean theta-band ERSP magnitudes at the specific
TF-ROI (4–7 Hz, 400–1000 ms) and S-ROI (frontal-central electrodes) in the four conditions (DI, DN, SI and SN). The congruency effect in the dual-
task condition was significantly smaller than that in the single-task condition. Panel B displays a scatter plot of the effect of WM on the interference
effect represented in RTs (X-axis) versus that represented in theta-band ERSP (Y-axis). A positive, linear relationship was evident and the
corresponding fitting line is shown (slope: .0015, p< .005).
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 99
each task condition (dual/single) was robust, with 27 out of
32 participants showing larger ERSP values in the
incongruent condition of the dual task, and 26 out of 32
participants showing larger ERSP values in the
incongruent condition of the single task. However, for the
interaction effect between Stroop congruency and Task,
exactly half of the participants showed the opposite
modulation effect to the rest of the participants. So it can
be concluded that in contrast to the theta band ERSP,
the alpha-related ERSP effects were simply mixed
(negative and positive) across participants. This resulted
in the overall diminished interaction effect between
Congruency and Task for the alpha rhythm.
Correlational analysis. Based on the results that
oscillations in the theta-band were related to the
interaction effect of congruency by task type, to further
validate the behavioral implications of theta-band
oscillations, we calculated the Stroop interference effect
(incongruent minus neutral) for every participant both on
RTs and on ERSP magnitude in the dual-task condition
and the single-task condition, respectively. By
subtracting the congruency effect in the dual-task
condition from that in the single-task condition
[(SI � SN) � (DI � DN)], we further calculated the
congruency effect difference between the single-task
and dual-task conditions. With these values, the
Spearman correlation coefficient between the behavioral
indices of congruency effect difference and the
corresponding ERS/ERD indices was calculated, and
the resulting correlation coefficient was tested against a
null hypothesis of no correlation at p< .05 (two tailed).
The result revealed that RTs[(SI�SN)�(DI�DN)] in the
behavior level was significantly positively correlated with
(SI � SN) � (DI � DN) in the EEG level as expressed in
theta-band ERSP magnitude (r= .36, p< .05). When
three outliers (maximum/minimum RT values and the
point with the largest residual error) were removed
(Glasauer et al., 2003), the correlation coefficient
increased and became extremely significant (r= .57,
p< .002, Fig. 3B. Fitting line: slope: .0015, p< .005).
Source localization analysis. As shown in Fig. 5, the
interaction effect of Stroop interference by Task type
was mainly located at the left middle frontal gyrus (BA
6; MNI coordinates: �24, �11, 64, Fig. 5).
Table 2. Theta rhythm (4–7 Hz) ERSP valuesa,b
Participant Dual (I � N)Dual Single (I � N)Single Interaction
I N I N
1 0.29 0.12 0.17 0.28 0.12 0.16 0.01
2 0.13 0.17 �0.05 0.11 0.04 0.06 �0.11
3 0.10 0.07 0.02 0.11 0.02 0.09 �0.07
4 0.21 0.31 �0.10 0.27 0.20 0.07 �0.17
5 0.11 0.08 0.03 0.15 0.10 0.06 �0.02
6 0.11 0.16 �0.05 0.30 0.19 0.11 �0.16
7 0.00 0.03 �0.03 �0.01 �0.04 0.04 �0.07
8 0.43 0.34 0.10 0.23 0.03 0.20 �0.10
9 0.30 0.14 0.16 0.27 0.16 0.11 0.06
10 0.22 0.29 �0.07 0.24 0.09 0.16 �0.22
11 0.06 0.12 �0.07 0.03 0.03 0.00 �0.07
12 0.42 0.31 0.11 0.34 0.13 0.22 �0.10
13 0.12 0.13 �0.01 0.18 0.09 0.09 �0.09
14 0.23 0.13 0.10 0.25 0.17 0.08 0.02
15 0.09 0.14 �0.05 0.37 0.16 0.21 �0.26
16 0.22 0.02 0.19 0.12 0.09 0.02 0.17
17 0.07 0.19 �0.12 0.07 0.06 0.01 �0.13
18 0.18 0.14 0.04 0.11 �0.17 0.28 �0.25
19 0.19 0.13 0.06 0.28 0.08 0.19 �0.13
20 0.17 0.28 �0.11 0.23 0.14 0.09 �0.20
21 0.10 0.14 �0.05 0.19 0.03 0.15 �0.20
22 0.22 0.25 �0.04 0.22 0.11 0.11 �0.15
23 0.07 0.05 0.02 0.23 0.28 �0.05 0.07
24 0.17 0.25 �0.08 0.07 �0.13 0.21 �0.28
25 0.05 �0.03 0.08 0.03 0.14 �0.11 0.19
26 0.14 0.12 0.02 0.06 0.13 �0.07 0.08
27 0.24 0.19 0.06 0.15 0.06 0.09 �0.04
28 0.17 0.05 0.12 0.19 0.19 0.00 0.12
29 0.29 0.22 0.07 0.26 0.36 �0.10 0.17
30 0.04 0.16 �0.11 0.09 0.09 �0.01 �0.11
31 0.17 0.08 0.08 0.31 0.14 0.18 �0.10
32 0.21 0.19 0.02 0.45 0.36 0.09 �0.07
Mean 0.17 0.16 0.02 0.19 0.11 0.09 �0.07
a Individual theta-band ERSP values for incongruent and neutral trials in the single/dual-task conditions.b I = incongruent; N = neutral.
100 Y. Zhao et al. / Neuroscience 262 (2014) 92–106
DISCUSSION
Previous studies found that concurrent WM tasks can
increase or decrease interference effects as evidenced
in behavioral RT data in various cognitive control tasks
(de Fockert et al., 2001; Kim et al., 2005; Park et al.,
2007; Gil-Gomez de Liano et al., 2010; Zhao et al.,
2010; Ahmed and de Fockert, 2012). In the present
study, we validated that a concurrent visual short-term
WM task could decrease the interference effect by using
the Chinese Stroop task with hand-drawn lines to be
maintained in visual WM. Behaviorally, we observed the
Stroop interference effect tended to decrease with the
concurrent WM task. Time–frequency analysis revealed
that after Chinese Stroop stimuli onset, the concurrent
WM task specifically modulated the congruency effect in
the theta-band ERSP magnitude, while having no effect
on the congruency effect in the alpha-band ERSP
magnitude. Further, the modulation of the Stroop
interference effect by concurrent WM expressed in
theta-band ERSP was correlated with behavioral RTs,
and source localization identified the modulation can be
mainly explained with the source located in the middle
frontal gyrus.
Dovetailing with general assumptions of multiple
resource theory (Navon and Gopher, 1979; Egner et al.,
2007; Egner, 2008), the interference effect on RTs of
the Chinese Stroop task tended to decrease when
performed concurrently with a visual short-term WM
task. The Chinese Stroop task differs from the English
Stroop task because Chinese characters rely heavily on
a specific visual system dedicated to form/shape
processing (Van Orden et al., 1988; Plaut et al., 1996;
Zhou and Marslen-Wilson, 1996, 2000), whereas color
processing relies on another comparatively independent
system in which only color information can be stored
and manipulated (Wheeler and Treisman, 2002; Kim
et al., 2005; Olsson and Poom, 2005). Thus the
concurrent visual short-term WM maintenance demands
(imitative structures as Chinese characters) occupied
the resources for Chinese characters processing, which
in their existing configuration facilitated the performance
of the Stroop task. Although a few studies have
observed the same kinds of WM facilitation effect
Table 3. Alpha rhythm (8–12 Hz) ERSP valuesa,b
Participant Dual (I � N)Dual Single (I � N)Single Interaction
I N I N
1 0.32 0.08 0.25 0.46 0.25 0.21 0.04
2 0.20 0.26 �0.06 0.14 0.02 0.12 �0.18
3 0.06 0.01 0.05 �0.09 �0.11 0.02 0.02
4 0.21 0.18 0.03 0.15 0.17 �0.02 0.06
5 0.14 0.12 0.03 0.14 0.13 0.01 0.02
6 0.22 0.10 0.12 0.22 0.08 0.13 �0.02
7 0.02 �0.06 0.08 �0.01 �0.11 0.10 �0.02
8 0.22 0.12 0.10 0.07 0.01 0.07 0.04
9 0.19 0.03 0.17 0.16 0.11 0.05 0.12
10 0.00 0.03 �0.03 �0.06 �0.08 0.02 �0.05
11 0.07 �0.05 0.12 �0.03 �0.07 0.04 0.08
12 0.30 0.22 0.07 0.19 0.10 0.09 �0.01
13 0.30 0.23 0.06 0.16 0.14 0.01 0.05
14 0.26 0.07 0.18 0.25 0.12 0.13 0.06
15 0.16 0.05 0.10 0.26 0.01 0.24 �0.14
16 0.27 0.08 0.19 0.06 �0.01 0.07 0.12
17 0.21 0.36 �0.15 �0.06 �0.05 �0.01 �0.15
18 0.01 0.00 0.02 0.02 �0.10 0.11 �0.10
19 0.43 0.15 0.28 0.21 0.10 0.11 0.17
20 0.04 �0.06 0.10 �0.12 �0.08 �0.04 0.14
21 0.06 0.05 0.01 0.12 0.06 0.06 �0.05
22 0.13 0.15 �0.02 0.15 0.08 0.08 �0.10
23 �0.01 0.03 �0.04 0.05 0.08 �0.02 �0.01
24 0.43 0.33 0.10 0.31 0.06 0.26 �0.15
25 �0.05 �0.12 0.07 �0.03 �0.08 0.05 0.03
26 0.10 0.05 0.05 0.08 �0.02 0.11 �0.06
27 0.40 0.07 0.34 0.26 0.15 0.11 0.23
28 0.13 0.01 0.02 0.26 0.07 0.19 �0.16
29 0.11 0.06 0.05 �0.09 �0.04 �0.05 0.10
30 �0.06 �0.09 0.03 0.11 0.03 0.08 �0.05
31 0.19 0.00 0.19 0.05 0.13 �0.07 0.26
32 0.13 0.06 0.06 0.30 0.19 0.11 �0.05
Mean 0.16 0.08 0.08 0.12 0.04 0.07 0.01
a Individual alpha-band ERSP values for incongruent and neutral trials in the single/dual-task conditions.b I = incongruent; N = neutral.
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 101
(e.g., Kim et al., 2005; Park et al., 2007; Zhao et al.,
2010), our research is at present the first report to have
directly observed this effect with typical Stroop tasks.
However, the modulation effect in RTs was still rather
small. Only after being corrected for the interference
effect as proportions of baseline RTs following Maylar
and Lavie’s routine did the modulation effect approach
significance (p= .06) (Maylor and Lavie, 1998). This
suggests that the effect size of modulation on the typical
Stroop interference effect by WM may be genuinely
small. This may be why previous publications have
never reported such an effect.
In relation to EEG results concerning the Stroop task,
paralleling the Hanslmayr et al. (2008) study, both theta-
& alpha-band ERSP increased significantly in the
incongruent condition compared with the neutral
condition in the single Stroop task. Stronger theta and
alpha-band ERSP magnitude emerged in a relatively late
period, extending from 400 to 1100 ms, implying their
potential involvement in a late response interference
resolution period. In accordance with this, theta-band
activity has been linked to multiple cognitive processes
including memory, attention, learning, performance
monitoring, and action selection (Bas�ar-Eroglu et al.,
1992; Wu et al., 2007; Cavanagh et al., 2012; Tang et al.,
2013). It was thus reasonable to conclude that theta
dynamics in the centro-frontal electrode regions reflected
a non-specific brain process such as the activation of
central executive processes which was important for WM,
attention, and cognitive control (Hanslmayr et al., 2008;
Cavanagh et al., 2012). On the other hand, recent studies
suggest that alpha rhythm is more likely to reflect cortical
inhibition in situations where participants have to inhibit
task-irrelevant information intake such as in mental
calculations, WM tasks or in situations where a response
must be withheld (Klimesch et al., 2007; Palva and
Palva, 2007). The increased fronto-central alpha-band
oscillations in the incongruent condition in our study were
consistent with the alpha rhythm’s inhibition hypothesis,
no matter whether explained in terms of more focused
attention (less task-irrelevant information intake) or
response inhibition.
However, when participants performed the Stroop
task with concurrent WM demands, the difference
between the incongruent and neutral condition in theta-
band ERSP magnitude reduced and this reduction was
robust, as shown in Fig. 4 and Table 2. Furthermore,
such a reduction was in accordance with the reduced
Stroop interference effect in the dual-task condition. The
congruency effect difference [(SI � SN) � (DI � DN)]
represented in theta-band ERSP magnitude and its
counterpart in behavioral RTs were positively correlated,
suggesting that theta-band ERSP magnitude was
modulated in the same way as behavioral RTs by
concurrent WM demands. Thus the reduced theta-band
ERSP difference may be the neural correlate of the
reduced Stroop interference. As visual WM demands
drained away the resources for Chinese character
(distractor) processing, the interference effect reduced
and there was no need for participants to actively
maintain the Stroop target and ignore the distractor in
the incongruent condition, thus theta-band oscillations,
which reflected the central process of active control,
reduced compared with the single Stroop task condition.
Source localization results using the LORETA method
suggest that current density activity in the dorsolateral
PFC (the left middle frontal gyrus) can explain the
reduced theta-band ERSP difference in the dual-task
condition. In line with the aforementioned theta-band’s
function in the central process of active control, the
middle frontal gyrus has been documented to be
involved in the cognitive control processes (Milham
et al., 2001; Kerns et al., 2004) and many researchers
suggest it is further involved in WM processes
(McCarthy et al., 1994; Cohen et al., 1997; Courtney
et al., 1997; Markov et al., 2010), which, in turn,
validated the overlap of cognitive control and WM.
In contrast to the reduced incongruent-neutral
difference in theta-band ERSP under the dual-task
condition, the alpha-band ERSP effect, on the other
hand, remained stable under the concurrent WM
demands. The alpha-band’s dissociation with theta-band
rhythm suggests that although both frequency bands’
ERSP increased in the incongruent condition of the
Fig. 4. Box plots of theta-band ERSP magnitude results plus original data. This figure shows the box plots of theta-band ERSP magnitudes at the
specific TF-ROI (4–7 Hz, 400–1000 ms) and S-ROI (frontal-central electrodes) in the four conditions (DI, DN, SI and SN). Box plots show the
median (central horizontal line), interquartile range (the 25th to the 75th percentile [box]), and ‘‘whiskers’’ (whiskers represent the smallest and
largest points inside 1.5 times the interquartile range, which respectively spread out from the first and third quartiles). Original data points are shown
beside the box plots. Note the data points in a specific condition are randomly jittered to make it easier to see individual values.
102 Y. Zhao et al. / Neuroscience 262 (2014) 92–106
single Stroop task, their functional relevance may be
different. Theta-band rhythm, as stated above, is
generally considered to be involved in central executive
processes. The role of alpha rhythm, on the other hand,
is far from conclusive. While many researchers in recent
years have realized occipital alpha rhythm plays an
important role in sensory suppression in selective
attention (for a review, see Foxe and Snyder, 2011), a
few researchers have also reported the involvement of
frontal alpha in cognitive/attentional control (Hanslmayr
et al., 2008; Mathewson et al., 2011; Tang et al., 2013).
Thus the function of alpha rhythm may be different with
respect to the scalp regions and specific tasks at hand.
Referring to the current research, the Stroop interference
and theta-band incongruent/neutral difference reduction
in the dual-task condition indicates the Stroop
interference between target colors and distractive
characters had reduced, due to the concurrent WM
demands draining away the specific resources for
character processing. So the only difference between
incongruent and neutral trials in the dual condition was
the residual interference, as can be seen in behavioral
RTs, where RTs for incongruent trials were still longer
than those for neutral trials. Thus the larger frontal
alpha ERSP amplitude in the incongruent trials cannot
be interpreted with other factors, except in terms of
cognitive control. In the same line of thought, the
dissociation between alpha and theta rhythms may not
necessarily imply the two rhythms’ functional separation,
but in fact implies that while both rhythms play a role in
cognitive control, their sensitivity to the perturbation of
cognitive control may be different. It is still quite possible
that the functional roles of frontal alpha and frontal theta
activities would be different in the microscale. Future
research making use of electrocorticograms or single-
cell recording would be needed to illustrate this further
(Jacobs and Kahana, 2010).
Despite its possible implications, this research has
three limitations that serve as foundations for further
work. First, the current experimental design may not be
so optimal studying the effect of concurrent WM on
cognitive control. A more traditional and popular way to
manipulate the WM factor is to set a low-load control
condition in which participants just need to remember
one object (de Fockert et al., 2001). Thus any difference
between the low-load and high-load condition can be
more confidently attributed to WM per se. Our current
design cannot exclude the potential explanation that the
possible visual encoding period before the Stroop stimuli
in the dual-task condition caused all of the effect that we
observed, although the paradigms we adopted here
have also been previously used for the study of WM
effects (Kim et al., 2005; Park et al., 2007; Gil-Gomez
de Liano et al., 2010; Zhao et al., 2010; Spronk and
Jonkman, 2012). To identify whether we successfully
manipulated the WM factor, we conducted another
supplementary behavioral experiment which was nearly
the same as the original design except that an
additional ‘‘simultaneous presentation condition’’ was
added, in which four structures were presented
simultaneously (similar to a flanker task) with the Stroop
task-related stimulus. We believed that if the visual
encoding period plays a role, we would not observe any
difference between the ‘‘simultaneous presentation
condition’’ and the original ‘‘dual-task condition’’. The
results showed the opposite. Briefly, with four structures
presented simultaneously with the Stroop stimulus, the
interference effect of the Stroop task tended to increase,
rather than decrease, compared with the single Stroop
task (Fig. 6). Thus, we believe our design, although not
perfect, was sufficient to successfully manipulate WM
per se. Future researchers could use a high/low load
contrast to perfect this study.
Second, the selection of S-ROI and TF-ROI, although
following some objective criteria (see ‘Experimental
procedures’) which had been used in previous
publications (Hu et al., 2013; Tang et al., 2013), was still
to some extent arbitrary. Future researchers could use
more objective cluster-based TF-ROI defining methods
(Zhang et al., 2012).
Third, we used LORETA to localize the sources of
observed scalp EEG activity. Although source
localization has proved to be as accurate in some
conditions as MRI or positron emission tomography
(Brodbeck et al., 2011), it is still necessary to exercise a
degree of caution when trying to interpret the sources
Fig. 5. The difference LORETA map for the Stroop congruency and Task type interaction effect. This figure shows the difference LORETA map for
the Stroop congruency and Task type interaction effect [(Single & Incongruent – Single & Neutral) – (Dual & Incongruent – Dual & Neutral)]. The
maximum activation was located at the left middle frontal gyrus (BA 6, MNI coordinates: �24, �11, 64).
Y. Zhao et al. / Neuroscience 262 (2014) 92–106 103
obtained, as the inverse problem is an inherent hard nut in
source localization. Future researchers could use high-
density electrode scalps (>100) and a realistic head
model to better their source localization results
(Brodbeck et al., 2011).
CONCLUSION
In sum, with a typical Chinese version of the Stroop task,
we observed that concurrent visual short-term WM
demands decrease the Stroop interference effect in RTs
and theta-band ERSP, supporting the multiple resources
theory of WM. The different modulation effects of WM
on theta and frontal alpha rhythm further suggests that
although frontal alpha rhythm is also involved in the
Stroop task, it functions in a way more robust to
perturbations of cognitive control.
Acknowledgments—This work was supported by the National
Natural Science Foundation of China (31170980, 81271477),
the Foundation for the Author of National Excellent Doctoral Dis-
sertation of PR China (201107), the New Century Excellent Tal-
ents in University (NCET-11-0698), and the Fundamental
Research Funds for the Central Universities (SWU1009001).
We thank Wei-Wei Peng for her generous suggestions in data
analysis and Yi-fan Li for his patient help in instructing the elec-
tronic artwork.
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(Accepted 24 December 2013)(Available online 7 January 2014)
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