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RESEARCH ARTICLE
Line and word bisection in right-brain-damaged patients with leftspatial neglect
Laura Veronelli • Giuseppe Vallar •
Chiara V. Marinelli • Silvia Primativo •
Lisa S. Arduino
Received: 6 February 2013 / Accepted: 27 September 2013 / Published online: 22 October 2013
� Springer-Verlag Berlin Heidelberg 2013
Abstract Right-brain-damaged patients with left unilate-
ral spatial neglect typically set the mid-point of horizontal
lines to the right of the objective center. By contrast, healthy
participants exhibit a reversed bias (pseudoneglect). The
same effect has been described also when bisecting ortho-
graphic strings. In particular, for this latter kind of stimulus,
some recent studies have shown that visuo-perceptual
characteristics, like stimulus length, may contribute to
both the magnitude and the direction bias of the bisec-
tion performance (Arduino et al. in Neuropsychologia
48:2140–2146, 2010). Furthermore, word stress was shown
to modulate reading performances in both healthy
participants, and patients with left spatial neglect and neglect
dyslexia (Cubelli and Beschin in Brain Lang 95:319–326,
2005; Rusconi et al. in Neuropsychology 18:135–140, 2004).
In Experiment I, 22 right-brain-damaged patients (11 with
left visuo-spatial neglect) and 11 matched neurologically
unimpaired control participants were asked to set the sub-
jective mid-point of word letter strings, and of lines of
comparable length. Most patients exhibited an overall dis-
proportionate rightward bias, sensitive to stimulus length,
and similar for words and lines. Importantly, in individual
patients, biases differed according to stimulus type (words
vs. lines), indicating that at least partly different mechanisms
may be involved. In Experiment II, the putative effects on the
bisection bias of ortho-phonological information (i.e., word
stress endings), arising from the non-neglected right hand
side of the stimulus were investigated. The orthographic cue
induced a rightward shift of the perceived mid-point in both
patients and controls, with short words stressed on the
antepenultimate final sequence inducing a smaller rightward
deviation with respect to short words stressed on the penul-
timate final sequence. In conclusion, partly different mech-
anisms, including both visuo-spatial and lexical factors, may
support line and word bisection performance of right-brain-
damaged patients with left spatial neglect, and healthy
participants.
Keywords Unilateral spatial neglect � Word
bisection � Line bisection � Word stress � Lexical
variables � Neglect dyslexia
Introduction
When setting the mid-point of horizontal lines, right-brain-
damaged patients with left unilateral spatial neglect
L. Veronelli � G. Vallar
Department of Psychology, Universita di Milano-Bicocca,
Milan, Italy
L. Veronelli (&)
Department of Neurorehabilitation, Casa Cura Policlinico,
Via Dezza 48, 20144 Milan, Italy
e-mail: [email protected]
G. Vallar
Neuropsychological Laboratory, IRCCS Istituto Auxologico
Italiano, Milan, Italy
C. V. Marinelli � S. Primativo
Department of Psychology, La Sapienza Universita di Roma,
Rome, Italy
C. V. Marinelli � S. Primativo
Neuropsychological Research Centre, IRCCS Foundation
Hospital Santa Lucia, Rome, Italy
L. S. Arduino
Universita LUMSA, Rome, Italy
L. S. Arduino
ISTC-CNR, Rome, Italy
123
Exp Brain Res (2014) 232:133–146
DOI 10.1007/s00221-013-3726-7
typically transect the line to the right of the objective mid-
point, ipsilateral to the side of the hemispheric lesion
(ipsilesional, see e.g., Bisiach et al. 1976, 1983). The
rightward bisection bias is a main manifestation of the
syndrome of unilateral spatial neglect (Vallar 1998;
Bisiach and Vallar 2000; Vallar and Bolognini 2013),
reflecting a defective perceptual representation of the lat-
eral extent of the line, which is interpreted as truncated, or
disproportionately compressed in the side contralateral to
the hemispheric lesion (contralesional), namely the left
hand side in right-brain-damaged patients (Bisiach et al.
1983; Bisiach and Vallar 2000). On the contrary, healthy
participants show a leftward bias (pseudoneglect), which
may reflect a leftward orientation, supported by a relative
prevalence of a leftward attentional bias by the right
hemisphere, and modulated by a number of factors,
including age and scanning direction (Bowers and Heilman
1980; Jewell and McCourt 2000, for review).
In recent years, the bisection task has been considered a
useful paradigm for investigating spatial representations,
not only of lines (e.g., Bisiach et al. 1976; Vallar et al.
2000; review in Jewell and McCourt 2000), but also of
written words (i.e., meaningful letter strings). Neurologi-
cally unimpaired participants show a leftward bias (i.e.,
pseudoneglect), when bisecting orthographic material,
including words, pseudowords (i.e., legal, pronounceable,
non-words), letter, and symbol strings (Fischer 1996,
2000). Automatic lexical access may involve an attentional
focusing on the word beginning (Fischer 1996, 2000,
2004), in order to establish a cohort of potential entries in
the mental lexicon (Paap et al. 1982). Consequently, par-
ticipants who read from left to right, may over-attend/
represent the lateral extent of the initial part of the word,
with a systematic leftward bias, when bisecting the letter
string (Attentional Scaling Hypothesis; Fischer 1996, 2000,
2004). This spatial distortion could be even partially
responsible for the leftward bias in oculomotor behavior
during reading tasks: The optimal viewing position may be
located just to the left of the middle of the word, reducing
gaze duration, lexical decision, and word reading time
(O’Regan et al. 1984; O’Regan and Jacobs 1992).
Stimulus length influences the bisection performance of
Italian healthy participants in a different fashion for lines
and orthographic strings (Arduino et al. 2010): Leftward
biases for short and long lines, and a more varied pattern
for orthographic strings (mainly, leftward biases for long
words, pseudowords, consonant, and symbol strings;
rightward biases for short such stimuli). Word and line
bisection may then undergo different types of processing
not only linguistic, but also visuo-perceptual, based on the
different structural and perceptual features of the two types
of stimuli, namely discrete (letter strings), for words, ver-
sus continuous, for lines. In one study (Lee et al. 2004; see
also Na et al. 2000, for a detailed description of the stim-
uli), Korean right-brain-damaged patients with left spatial
neglect and neurologically unimpaired participants circle
the target closest to the mid-point of long linear arrays (24
targets and 21 distracter in a 242-mm string) of character
and symbol strings. All participants exhibit a rightward
deviation (greater in right-brain-damaged neglect patients)
with both character and symbol strings, as compared with
solid lines. In another study (Mohr and Leonards 2007),
native English healthy participants show greater rightward
biases, when bisecting long letter strings, in which emo-
tional (as compared to neutral) words are inserted on the
right or on the left of the veridical center. This rightward
deviation may be explained by a left-hemispheric activa-
tion, related to greater demands on left-hemisphere-sup-
ported attentional resources, devoted to local processing
(Martin 1979). In the case of real words, inserted in letter
strings, lexical-semantic processing may also contribute to
a left-hemispheric activation (see Bowers and Heilman
1980).
Due to the few available neuropsychological studies on
word bisection, we first aimed at assessing, in Italian right-
brain-damaged patients with left spatial neglect, whether
stimulus length modulates the error in a similar way as that
reported for line bisection, namely a greater rightward
deviation with longer lines (see, e.g., Bisiach et al. 1983;
Vallar et al. 2000; Daini et al. 2002, for such an evidence in
right-brain-damaged patients from line bisection perfor-
mance). Accordingly, we predicted a greater rightward bias
for long words than for short ones. Secondly, with word
and line bisection involving partially independent mecha-
nisms (see Arduino et al. 2010), double dissociations
(Vallar 2000) may be predicted in the patients’ perfor-
mances with respect to the line and word stimuli. Specifi-
cally, unilateral spatial neglect may impact on the bisection
of words and lines in a different fashion in different
patients, supporting the existence of independent mecha-
nisms, which could be compromised selectively by brain
damage.
Secondly, we aimed at investigating the effects of the
lexical status of the stimulus on the magnitude of the bias.
Lexical variables modulate the reading performance of
brain-damaged patients with unilateral spatial neglect
(review in Vallar et al. 2010). As for word bisection, no
effects of word written frequency have been found so far
(Arduino et al. 2010; Fischer 1996).
In Italian, word stress is a good candidate to exploit the
influence of lexical factors in the patients’ reading perfor-
mance, since the main source of information for setting
word stress position is to look at their final (right-sided)
part (Burani and Arduino 2004). Right-brain-damaged
patients with left neglect dyslexia are able to read aloud
letters in the right hand side of a word. Results from both
134 Exp Brain Res (2014) 232:133–146
123
healthy participants, and patients with left spatial neglect
and neglect dyslexia, show that word stress modulates
reading (Cubelli and Beschin 2005, the presence of an
accent mark; Rusconi et al. 2004, preserved stress position
in the response). Italian words with three or more syllables
have two main stress patterns: They can be stressed on the
penultimate (last but one) syllable (e.g., matıta, pencil), or
on the antepenultimate (last but two) syllable (e.g., bıbita,
drink), with the former being the more frequent stress
pattern (dominant or regular), the latter the less frequent
one (non-dominant or irregular). Different word final
sequences show different proportions of words with dom-
inant or non-dominant stress. For instance, most words
ending in -oro are regularly stressed on the penultimate
syllable (about 81 %), with only 19 % of words taking the
irregular stress. The final word sequence could then be used
by Italian readers as an informational cue for attributing the
correct word stress pattern (Burani and Arduino 2004;
Sulpizio et al. 2013). This, in turn, may modulate the
bisection performance of right-brain-damaged patients with
left spatial neglect. Based on the above-mentioned evi-
dence suggesting that stress information modulates reading
performance, the rightward bisection bias for words stres-
sed on the antepenultimate syllable, as compared with
words stressed on the penultimate syllable may be reduced,
both in brain-damaged neglect patients, as well as in
healthy participants.
Experiment I
Materials and methods
Participants
Participants were recruited from the inpatient population of
the Fondazione S. Lucia IRCCS, Rome (Research Center
on Neuropsychology), and from the Casa Cura Policlinico,
Milan (Department of Neurorehabilitation), Italy. A total of
11 right-hemisphere-damaged patients with left unilateral
spatial neglect (N?), 11 right-hemisphere-damaged
patients without left spatial neglect (N-), and 11 unim-
paired control participants (C) took part in the study. The
N? patients had suffered a stroke (10 ischemic, 1 ischemic
with hemorrhagic infarction). The sample included 4
females and 7 males with a mean age of 67.90 years
(SD = ±9.25, range 48–79), and a mean education of
9.81 years (SD = ±5.19; range 5–18). Mean duration of
disease of the 11 patients was 2 months (SD = ±1.46,
range 1–6). In the N- group, 9 patients had suffered an
ischemic stroke and 2 an ischemic stroke with hemorrhagic
infarction. The sample included 4 females and 7 males
(mean age = 69.82 years, SD = ±9.97, range 44–79;
mean education = 11.27 years, SD = ±4.90, range 2–18).
The mean duration of the disease was 1.41 months
(SD = ±.70, range 1–3). C participants were matched for
sex (6 females), age (mean = 68.73 years, SD = ±7.56,
range 57–80), and education (mean = 10.73 years,
SD = ±3.90, range 5–17) with the patients. One-way
analyses of variance (ANOVAs) showed that age
(F2,30 = .12; p = .88; pg2 = .01) and educational level
(F2,30 = .27; p = .77; pg2 = .02) did not differ among
groups (N?, N-, and C). Furthermore, duration of the
disease did not differ between N? and N- patients
(t20 = 1.21; p = .24). Lesion site was assessed for each
right-brain-damaged patient by CT or MRI scan and drawn
manually using the MRIcro software (Rorden and Brett
2000) onto selected horizontal slices of a standard template
brain. Figure 1 shows the overlapped lesion maps of 21 out
of 22 right-brain-damaged patients (N? and N- groups).
Scan images were unavailable for N- patient RL, with
neuroradiological medical records reporting an ischemic
lesion involving the right fronto-temporal region and the
insula. In N? patients lesions superimposed in the right
putamen and in the white matter underneath the insula, the
rolandic operculum and the frontal-inferior operculum (11
patients); in N- patients a maximum overlap was observed
in the white matter underneath the insula (5 patients).
Average lesion volume (SD) was greater in N? patients
(105.16 cm3 ± 73.61) than in N- patients (17.31 ± 15.37;
t11 = 3.87, p = .003), in line with previous findings
(Cattaneo et al. 2012; Leibovitch et al. 1998).
Patients were right-handed on a standard questionnaire
(Oldfield 1971), had normal or corrected-to-normal
vision, and no history of previous neurological and
psychiatric disorders. All patients showed preserved
visual fields on Goldmann perimetry or on the confron-
tation test, but N? patient MA, who exhibited left
hemianopia. All patients were given a Mini Mental State
Examination (MMSE, Folstein et al. 1975) and their
scores (N?: mean 26.53, SD ±1.28, range 25–29; N-:
26.76 ± 1.91, range 25–30) were above the adjusted
cutoff of Magni et al. (1996). Demographic and neuro-
logical information for N? and N- patients are sum-
marized in Table 1. Informed consent was obtained from
all participants (Declaration of Helsinki, British Medical
Journal, 302: 1194, 1991).
Baseline neuropsychological assessment
The presence and severity of left spatial neglect were
assessed by a diagnostic battery, which included: line
(Albert 1973), letter (Diller and Weinberg 1977; Vallar
et al. 1994), and star (Wilson et al. 1987; Ronchi et al.
2009) cancellation; line bisection (Fortis et al. 2010);
complex figure drawing (Gainotti et al. 1972; Ronchi et al.
Exp Brain Res (2014) 232:133–146 135
123
2009); clock drawing from memory (Mondini et al. 2003);
sentence reading (Zoccolotti et al. 1989). Finally, a single
word reading test was given. Stimuli included two lists of
38 words and 38 orthographically pseudowords (Vallar
et al. 1996). Stimuli were presented separately in a random-
fixed order, with a time-limited computerized procedure.
Participants sat about 50 cm away from a 15.400 PC screen
in a quiet room, with the center of the screen being aligned
with the mid-sagittal plane of the participant’s body.
E-Prime v 2.0 software was used to display the stimuli.
Each trial began with a 300-ms fixation point (a cross,
black, 30-pt, Arial font) followed by the appearance of a
single word (black letters uppercase, 37-pt, Arial font) in
the center of the screen, with a 500-ms exposure. The
participant’s task was to read aloud each letter string, with
answers being manually registered by the experimenter. If
a participant failed to read correctly all of the first 5 stimuli
or 8 out of the first 10 stimuli, time exposure was increased
to 750 ms. In case of failure with this time exposure of the
stimulus (scored with the same criteria), a 1,000-ms
exposure was used. No feedback was given as for the
participant’s accuracy. Errors were classified as ‘‘neglect’’
errors using the ‘‘neglect point’’ criterion of Ellis et al.
(1987). A pathological score in at least one test was con-
sidered as an index of spatial neglect. Table 2 shows the
results of the baseline assessment. Notably, pseudoword
reading performance resulted a more sensible indicator of
neglect dyslexia, as compared with word reading (Vallar
et al. 2010, for review; Martelli et al. 2011).
Stimuli
Three sets of 20 Italian nouns were selected from a corpus
of Italian written language of 3 million tokens (Laudanna
et al. 1995). Words varied in length (5–10–13 letters), and
had a medium word token frequency of 81 (range 5–304).
All words were morphological simple, with the dominant
(or regular) stress pattern and without double consonants or
contextual rules. For 5- and 10-letter words, stimuli were
Fig. 1 Superimposition of the right-hemispheric lesions in 11 right-
brain-damaged N? patients (a) and in 10 right-brain-damaged N-
patients (b). MNI coordinates for the shown axial slices are given.
The number of overlapping lesions is indicated by different colors,
coding increasing frequencies (from violet, n = 1, to red, n = 11).
Regions specifically damaged in right-brain-damaged N? patients
mainly involved the right putamen and the white matter underneath
the insula, the rolandic operculum and the frontal-inferior operculum
Table 1 Demographic and neurological data of 11 right-brain-dam-
aged N? patients and 11 right-brain-damaged N- patients
Patient Sex/age/
education
Etiology/lesion
site
Duration of disease
(months)
N?
DF F/69/8 I/TFP 1
MV M/79/5 I/FT In 2
BA M/68/5 I/TF In 1
PF M/70/17 I/FTO In 2
LE F/72/13 I/P 1
LA M/74/5 I/P 1
DMF M/57/8 I/ FP In ic 1
MP M/61/8 I/TFP 2
GP F/78/5 I/T In Bg 2.5
MA M/48/16 I/PTO 2.5
VI F/71/8 I H/TFP 6
N-
DI F/44/13 I H/FT In Bg 1
CE M/78/13 I/P 1
DA M/75/13 I/ic 1
LG M/67/18 I H/ic Bg 1.5
RA M/73/10 I/P 2.5
VA M/61/13 I/t ic 1
RL M/70/8 I/FT In 1.5
FA F/76/2 I/ec Bg 1
LL M/73/5 I/P 3
PG F/72/11 I/TP 1
FMT F/79/18 I/Bg 1
M/F male/female, I/H ischemic/hemorrhagic lesion, F frontal,
P parietal, T temporal, O occipital, In insula, ic internal capsule, ec
external capsule, Bg basal ganglia
136 Exp Brain Res (2014) 232:133–146
123
no-suffixed nouns, while for 12- or 13-letter words very
few suffixed nouns were included, due to the lack of a
sufficient number of no-suffixed Italian words matched for
length (see ‘‘Appendix’’). All 3 categories of stimuli were
approximately matched for number and position (initial vs.
final) of ascending and descending letters (Fischer 1996).
Each word was printed in lowercase, 54-pt, Arial font. The
following word lengths (mean mm ± SD, range) were
used: 44.6 ± 5.6, 34–55, for 5-letter words; 88.2 ± 6.9,
75–100, for 10-letter words; 104.4 ± 7.9, range 94–126,
for 13-letter words. The distance between the leftward
extremity of the first letter and the rightward extremity of
the last letter was measured to the nearest millimeter.1 A
total of 60 lines (2-pt, 1 mm in width) matched one by one
for length (in millimeter) with the words were designed.
Procedure
Stimuli, both words and lines, were presented in the center
of an A4 horizontally oriented sheet, each page containing
four stimuli located one above the other, with the center of
the sheet being aligned with the mid-sagittal plane of the
participant’s body at a viewing distance of about 40 cm. A
moveable window was used in order to present each
stimulus one at a time. Participants were free to move their
head and eyes throughout the task.
Words and lines were divided into two parts, in which
the three lengths were equally represented. An ABBA
order (words-lines-lines-words) was used for half of the
Table 2 Baseline assessment for left visuo-spatial neglect
Line
cancellation
Letter
cancellation
Star
cancellation
Sentence
reading
Complex figure
drawing
Line
bisection
Clock
drawing
Single word reading
L R L R L R Word Non-word
N?
DF 9/11a 0/10a 53/53a 47/51a 5/30a 0/26a 5/6a 2/5a -6.44 9/10 0 (0/2) .57 (4/7)b
MV 6/11a 0/10a 43/53a 20/51a 30/30a 8/26a 5/6a 3/5a 21.36a 7/10 0 (0/2) .5 (2/4)
BA 0/11 0/10 33/53a 7/51a 0/30 1/26 1/6a 1/5a 13.36a 3/10a 0 (0/1) .33 (4/12)
PF 0/11 0/10 6/53a 3/51a 0/30 1/26 0/6 0/5 4.16 7/10 0 (0/1) .2 (3/15)
LE 8/11a 0/10a 24/53a 16/51a 2/30a 0/26a 1/6a 0/5 12.51a 9/10 0 (0/2) .22 (2/9)
LA 0/11 0/10 34/53a 5/51a n.a. n.a. 1/6a 1/5a n.a. 2.5/10a .17 (1/6) 0 (0/12)
DMF 0/11 0/10 53/53a 31/51a 0/30 0/26 0/6 0/5 10.5a 2.5/10a 0 (0/0) 0 (0/4)
MP 7/11a 0/10a 39/53a 4/51a 15/30a 2/26a 5/6a 0/5 -5.18 10/10 1 (1/1) .5 (1/2)
GP 1/11a 0/10a 53/53a 47/51a 3/30 3/26 2/6a 0/5 -3.24 1/10a 0 (0/3) .21 (3/14)
MA 11/11a 1/10a 8/53a 0/51a 10/30 11/26 5/6a 0/5 16.22a n.a. .77 (10/13)b .91 (31/34)b
VI 4/11a 0/10a 53/53a 22/51a 30/30a 11/26a 4/6a 2/5a 3.89 3.5/10 0 (0/3) .29 (4/14)
N-
DI 0/11 0/10 0/53 0/51 1/30 0/26 0/6 0/5 2.81 9.5/10 0 (0/0) 0 (0/2)
CE 0/11 0/10 0/53 0/51 0/30 0/26 0/6 0/5 4.96 7/10 0 (0/7) .16 (3/18)
DA 0/11 0/10 0/53 0/51 1/30 0/26 0/6 0/5 5.54 10/10 0 (0/2) .16 (1/6)
LG 0/11 0/10 0/53 1/53 0/30 0/26 0/6 0/5 -1.93 9.5/10 0 (0/0) 0 (0/0)
RA 0/11 0/10 0/53 0/51 0/30 0/26 0/6 0/5 .99 7/10 0 (0/0) 0 (0/3)
VA 0/11 0/10 1/53 0/51 0/30 0/26 0/6 0/5 2.69 10/10 0 (0/0) 0 (0/1)
RL 0/11 0/10 2/53 3/51 1/30 0/26 0/6 0/5 3.51 9/10 0 (0/0) 0 (0/0)
FA 0/11 0/10 2/53 0/51 0/30 1/26 0/6 0/5 2.26 6/10 .28 (2/7) .14 (3/22)
LL 0/11 0/10 0/53 0/51 0/30 0/26 0/6 0/5 2.09 8.5/10 0 (0/2) 0 (0/3)
PG 0/11 0/10 0/53 8/51 2/30 3/26 0/6 0/5 3.39 6/10 0 (0/3) .31 (4/13)
FMT 0/11 0/10 0/53 0/51 0/30 0/26 0/6 n.a. 4.82 6.5/10 0 (0/0) 0 (0/2)
Cancellation tasks: number of omissions in the left/right (L/R) hand side of the display. Sentence reading: number of correct responses. Complex
figure drawing: 0/5 indicates errorless performance. Clock drawing: total score ranged from 0 to 10. Line bisection: deviation in millimeter (-/?
leftward/rightward deviation); percentage and number (in brackets) of neglect errors out of the total errors in word and non-word reading
n.a. not assesseda Defective performance, as compared with normative data, indicating left neglectb Neglect errors
1 In the case of words starting with the letters ‘‘t’’ and ‘‘f’’, the
measure began from the vertical bar rather than the horizontal one.
Exp Brain Res (2014) 232:133–146 137
123
patients, and a BAAB for the other half. The experiment
was performed in a single session. Patients were individ-
ually tested in a quiet room, with the experimenter sitting
in front of them. The patients’ task was to bisect each
stimulus, marking its mid-point with a pencil, using the
unaffected ipsilesional right hand. Participants were
informed that the bisection mark could be made in any
point of the word, irrespective of whether it might fall
between two letters or go through a letter. No time limits
were imposed, but participants were instructed not to count
letters. No feedback was given with respect to the accuracy
of the response. The distance between the left end of each
stimulus and the participant’s mark was measured to the
nearest millimeter. Each measure in millimeter was con-
verted into a standardized score (measured left half minus
objective half/objective half 9 100), in order to equate the
participants’ error with respect to stimulus length. This
percent deviation yielded positive values for rightward
deviations with respect to the objective mid-point of the
stimulus, negative values for leftward deviations (Rode
et al. 2006).
Statistical analyses
Average standardized scores were analyzed by repeated-
measures analyses of variance (ANOVAs), with two
within-subjects factors (type of stimulus and length), and
one between-subjects factor (the groups of participants). In
order to control for a possible effect of lesion size in
determining the amount of the patients’ bisection error, and
its direction, an analysis of covariance (ANCOVA) on the
mean deviations was carried out, with group (N?, N-) as
the between-subjects factor, type of stimulus and length as
the within-subjects factors, and lesion size as the covariate
(mean-centered prior to the analysis). The Greenhouse-
Geisser correction for repeated-measures analyses
(Greenhouse and Geisser 1959) was used, in order to cor-
rect for violations of the sphericity assumption whenever
necessary. For every analysis, we calculated the partial Eta
Squared (pg2), which measures the proportion of the total
variance that was attributable to a main factor or to an
interaction (Cohen 1973). Whenever necessary, pairwise
comparisons were performed with Student-Newman-Ke-
uls’ post hoc multiple comparisons. Mean bisection per-
formances were compared to accurate bisection through
one-sample t tests against zero. Subsequently, to assess for
any significant defective performance with different types
of stimuli in individual patients with left unilateral spatial
neglect, we compared the average deviation errors of each
patient in the word and line tests with the mean deviations
of healthy participants and of the N- patients. The anal-
yses were performed by t tests (Crawford and Garthwaite
2002), testing whether the score of an individual patient
was significantly different from the mean score of control
participants. Using the Revised Standardized Different Test
(Crawford and Garthwaite 2005), we also tested for each
patient whether the difference between the standardized
scores on word and line bisection was significantly dif-
ferent from the correspondent mean differences found in
the control samples. Finally, Pearson’s correlations, with
Bonferroni correction for multiple comparisons, were used
in order to measure the association between bisection
errors for words and lines in the three groups.
Results
Since a previous analysis showed the lack of significant
differences between medium and long stimuli for all
groups of participants, these two conditions were merged
together and compared with short stimuli. Figure 2 shows
the average percentage error by group (N?, N-, and C
participants), stimulus (words, lines), and lengths (short
and long). N? patients made a greater rightward mean
error with long stimuli with respect to short ones, as
compared to those made by N- patients and control
participants.
The ANOVA revealed significant main effects of length
(short, 5 letters; long, 10–13 letters) (F1,30 = 9.50;
p = .004, pg2 = .24), while the main effects of group (N?
patients, N- patients, and control participants)
(F2,30 = 2.56; p = .09; pg2 = .15) and type of stimulus
(words vs. lines) were not significant (F1,30 = .72;
p = .40; pg2 = .02). The length by group (F2,30 = 7.17;
p = .003; pg2 = .32) and the type of stimulus by length
(F1,30 = 5.49; p = .03; pg2 = .15) interactions were sig-
nificant. The type of stimulus by group (F2,30 = .05;
Fig. 2 Experiment I: mean percent deviation error (±SE) by group
[11 N? patients, 11 N- patients, and 11 control participants (C)],
stimulus type (words and lines), and stimulus length (short: light gray
column; long: dark gray column)
138 Exp Brain Res (2014) 232:133–146
123
p = .95; pg2 = .003) and the type of stimulus by length by
group (F2,30 = .62; p = .54; pg2 = .04) interactions were
not significant. Post hoc multiple comparisons revealed that
N? patients showed a ‘‘length effect,’’ with a mean smaller
rightward error in bisecting short (1.05 %) versus long
(10.55 %) stimuli. Average bisection scores of N- patients
did not differ by stimulus length (short: 1.57 % and long:
2.52 %), as well as those of C participants (short: -.005 %
and long: -.02 %). Rightward deviations made by N?
patients with long stimuli are larger than the biases
exhibited by N- and C participants with all types of
stimuli, both lines and words, with no significant differ-
ences for short stimuli. This means that N? patients
bisected long stimuli more to right when compared to both
C participants and N- patients. No significant differences
were found between lengths, when comparing the perfor-
mances of the N- and C groups. As the type of stimulus by
length interaction, while mean deviations for short words
(.74 %) did not differ from that for short lines (1.01 %),
mean deviations for long words (3.25 %) were smaller than
those for long lines (5.45 %): This means that long lines
were globally bisected more to the right than long words,
independently from the group of participants.
The ANCOVA revealed a significant main effect of the
covariate lesion size (F1,18 = 14.12; p = .001; pg2 = .44).
Importantly, the main effect of length (F1,18 = 9.49;
p = .006; pg2 = .35) and the length by group interaction
(F1,18 = 5.51; p = .03; pg2 = .23) were significant. The
main effect of type of stimulus, of group and all the other
interactions were not significant.
In the N? group, mean rightward bisection errors dif-
fered from zero (i.e., accurate bisection) for long lines
(11.44 %, t10 = 3.25, p = .009); they were almost signif-
icant for long words (9.65 %, t10 = 2.21, p = .05), while
no differences were found for the other types of stimuli:
short words (.50 %, t10 = .12, p = .90) and short lines
(1.60 %, t10 = .41, p = .69). In the N- group, mean
rightward bisection errors differed from zero for long
(4.08 %, t10 = 4.10, p = .002), but not for short (1.68 %,
t10 = 1.51, p = .16) lines, as well as for words of both
lengths (short: 1.46 %, t10 = 1.29, p = .23; long: .96 %,
t10 = .95, p = .36). In the C group, mean bisection errors
did not differ from zero for all types of stimulus.
The performances of the individual N? patients were
compared with those of both N- patients and C partici-
pants for long stimuli, since the above reported ANOVAs
had shown no differences between groups for short stimuli
(see Fig. 3). Comparing the difference between word and
line bisection in the individual patient with the same
average difference in the control groups (both N- patients
and C participants), patient MV bisected long lines more
rightwards than long words, while three patients out of 11
exhibited larger rightward displacements for long words
than for long lines (MP, GP, and MA).
In the C group, Bonferroni-corrected (p \ .008) Pear-
son’s correlations performed on bisection deviations were
significant between short and long words (r = .76,
p \ .008) and short and long lines (r = .81, p \ .008),
with all other correlations not attaining the significance
level. In the N? group, correlations were not significant for
all types of comparison, as well as in the N- group.
In sum, data from single-patient analyses concur to
suggest that left spatial neglect affects in a differential
fashion the patients’ bisection of words and lines.
Experiment II
As discussed in the Introduction, Italian words with three
or more syllables have two main stress patterns: they can
Fig. 3 Experiment I: mean percent deviation error by stimulus type
(words and lines) and length (long), made by each of the 11 N?
patients. The mean error (±SE) of the 11 N- patients and the 11 C
participants is shown in the bottom row. *Significant difference
between each patient’s score and the mean score of the C group for
each stimulus condition. **Significant difference between each
patient’s score and both the mean score of the N- and of the C
groups for each stimulus condition. Circle and brackets: significant
difference between word and line bisection in the individual patient,
compared to the average difference in the C group. Double circle and
brackets: significant difference between word and line bisection in the
individual patient, compared to both the average difference in the N-
and in the C groups
Exp Brain Res (2014) 232:133–146 139
123
be stressed on the penultimate (last but one) syllable (e.g.,
matıta, pencil, ‘‘dominant’’ stress pattern), or on the ante-
penultimate (last but two) syllable (e.g., bıbita, drink,
‘‘non-dominant’’ stress pattern). Moreover, also the final
letters of the word provide informational cues for attrib-
uting the correct word stress pattern. Accordingly, right-
brain-damaged patients with left neglect, who typically
attend the right hand side of a word more than the left hand
side, may manifest this effect, possibly even strongly (see
Daini et al. 2002, for related evidence the bisection per-
formance of the Brentano version of the Muller-Lyer by
right-brain-damaged neglect patients). In particular, the
rightward final sequence, which includes information as to
the probability that the word is stressed on the penultimate
or the antepenultimate syllable, could modulate bisection
accuracy: specifically, guessing that the word is likely to be
irregular, patients could orient toward its initial (left-sided)
letters, thus reducing the rightward, neglect-related, bias.
To this aim, both patients and neurologically unimpaired
control participants set manually the mid-point of words
with the two different stress patterns and final sequences,
which, as discussed earlier, can be used as orthographic
cues for predicting word stress.
Stimuli and procedure
The stimuli of Burani and Arduino (2004) were used.
Stimuli were divided into two lists, according to the type of
final sequences: (1) 30 words containing final sequences as
-oro, which characterized more regularly stressed words
(penultimate final sequence words); (2) 30 words contain-
ing final sequences as -ola, which characterized more
irregularly stressed words (antepenultimate final sequence
words). Stimuli were 6 to 9 letters long, and were of low
frequency (Istituto di Linguistica Computazionale
1989) (see ‘‘Appendix’’). As in Experiment I, each word
was printed in lowercase, 54-pt, Arial font: mean length of
the stimuli was 55.2 mm (SD = ±9.49, range 41–76) for
penultimate final sequence words, and 55.2 mm
(SD = ±10.57, range 42–73) for antepenultimate final
sequence words. Procedures and scoring modality were
identical to those of Experiment I.
Statistical analyses
The data were analyzed by repeated-measures ANOVAs
with a within-subjects factor (type of stimulus), and one
between-subjects factor (the three groups of participants).
Mean bisection performances were compared to accurate
bisection through one-sample t tests against zero. The
performances of the individual patients were analyzed by
t tests (Crawford and Garthwaite 2002), comparing each
patient score with the mean score of control participants.
Pearson’s correlations were carried out in order to measure
the association between errors for penultimate and ante-
penultimate final sequence words in the three groups of
participants.
Results
As shown in Fig. 4, all participants showed a greater rel-
ative rightward deviation with penultimate final sequence
words with respect to antepenultimate final sequence
words. The ANOVA revealed a significant main effect of
the type of stimulus (F1,30 = 5.91, p = .02, pg2 = .16),
while the main effect of group (F2,30 = .40; p = .67,
pg2 = .03), and the type of stimulus by group interaction
(F2,30 = 1.68; p = .20, pg2 = .10) were not significant. In
order to control whether length could have an effect even
with these types of stimuli, a post hoc analysis was con-
ducted dividing words by number of letters (6–7 letters vs.
8–9 letters). The ANOVA revealed a significant main
effect of length (F1,30 = 6.94, p = .01, pg2 = .19), while
the main effect of group (F2,30 = 1.42; p = .26,
pg2 = .09) and of the type of stimulus were not significant
(F1,30 = 1.91; p = .18, pg2 = .06). The length by group
(F2,30 = 13.37; p \ .001; pg2 = .47) and the type of
stimulus by length (F1,30 = 4.61; p = .04; pg2 = .13)
interactions were significant. The type of stimulus by group
(F2,30 = .18; p = .84; pg2 = .01) and the type of stimulus
by length by group (F2,30 = .35; p = .71; pg2 = .02)
interactions were not significant. Post hoc multiple com-
parisons revealed that N? patients showed a ‘‘length
effect,’’ with a mean smaller rightward error in bisecting
short (2.09 %) versus long (8.13 %) words, replicating
results of Experiment I. Average bisection scores of N-
patients did not differ by stimulus length (short: 1.80 %
Fig. 4 Experiment II: mean percent deviation error (±SE) by group
(N? and N- patients, and C participants), and by stimulus condition
(penultimate final sequences: dark gray column; ante-penultimate:
light gray column)
140 Exp Brain Res (2014) 232:133–146
123
and long: 2.08 %), as well as those of C participants (short:
.44 % and long -.99 %). No other comparisons were
significant. As the type of stimulus by length interaction,
the mean deviation for short antepenultimate final sequence
words (.32 %) was smaller than those for short penultimate
final sequence words (2.57 %), confirming the lexical
effect found in the previous analysis of variance for short
stimuli. The mean deviation for long antepenultimate final
sequence words (3.19 %) did not differ from those for long
penultimate final sequence words (2.95 %). Being a post
hoc analysis, the lack of lexical effect with long words
could be due to the fact that long stimuli are very few with
respect to short ones: the small number of items could be
insufficient to permit the emergence of such an effect.
However, caution is needed and more controlled studied
should be conducted in order to investigate the relationship
between lexical factors and length in word bisection.
In the N? group, the mean bisection error did not differ
from zero (i.e., accurate bisection) for both types of stimuli
(penultimate, 4.38 %, t10 = 1.09, p = .30; antepenulti-
mate: 1.92 %, t10 = .54, p = .60), as well as in the C group
(penultimate: .33 %, t10 = 2.88, p = .78; antepenultimate:
.16 %, t10 = .16, p = .87). In the N- group, penultimate
(2.42 %, t10 = 2.87, p = .02), but not antepenultimate
(1.31 %, t10 = 1.31, p = .22) final sequence words differed
from zero.
Comparing the mean shifts in the penultimate and ante-
penultimate final sequence word conditions for each patient,
with those of both N- patients and healthy participants,
patients GP and LA showed significant rightward biases for
both types of stimuli (GP penultimate, ?33.86 %,
N- patients: t10 = 10.75, p \ .001; healthy participants:
t10 = 8.51, p \ .001; GP antepenultimate, ?23.06 %,
N- patients: t10 = 6.25, p \ .001; healthy participants:
t10 = 6.79, p \ .001; LA penultimate, ?10.55 %,
N- patients: t10 = 2.78, p = .02; healthy participants:
t10 = 2.59, p = .02; LA antepenultimate, ?12.94 %,
N- patients: t10 = 3.34, p = .007; healthy participants:
t10 = 3.80, p = .003). BA exhibited leftward deviations for
both types of stimuli (penultimate, -23.74 %, N- patients:
t10 = -8.94, p \ .001; healthy participants: t10 = -6.11,
p \ .001; antepenultimate, -25.40 %, N- patients: t10 =
-7.68, p \ .001; healthy participants: t10 = -7.60, p \ .001).
Errors made by all other N? patients did not differ from those
of N- patients and healthy control participants (p [ .05, for
all comparisons). For patient GP, the difference between the
bisection errors in penultimate and antepenultimate final
sequence words was significant (t29 = 2.84, p = .008),
while for patient LA (t29 = .65, p = .52) it was not. Pear-
son’s correlations performed on bisection deviations were
significant between penultimate and antepenultimate final
sequence words in all groups of participants (N?: r = .95,
p \ .001; N-: r = .79, p \ .005; C: r = .88, p \ .001).
Discussion
The present study had the twofold aim of investigating:
(1) how perceptual and lexical features modulate the
bisection of orthographic strings in right-brain-damaged
patients and neurologically unimpaired control partici-
pants; (2) whether unitary or independent processes sup-
port the bisection of lines and orthographic material (see
for discussion of this issue Arduino et al. 2010). To these
aims, the effects of stimulus type (lines vs. words),
stimulus length (short vs. long), and lexical features (word
stress) on bisection accuracy were assessed. In Experiment
I (bisection of lines and words of different lengths), right-
brain-damaged patients with left spatial neglect make, as a
group, an average rightward error larger than those of
patients without neglect and healthy participants, and
show a length effect, with a greater rightward directional
bias for longer stimuli, comparable for lines and words.
These results are in line with previous findings from line
bisection tasks in right-brain-damaged patients with left
spatial neglect (see Bisiach et al. 1983; Marshall and
Halligan 1989; Vallar et al. 2000; Daini et al. 2002), and
extend them to the bisection of words. Furthermore, long
lines are bisected more rightwards when compared to long
words, independently from the group of participants. This
result is in line with previous findings on word bisection
(Fischer 1996, 2000), and could be attributed to reading
strategy activated by the type of stimulus (i.e., words)
even in patients with spatial neglect, possibly involving
automatic lexical access, which focuses attention on the
word beginning (Attentional Scaling Hypothesis; Fischer
1996, 2000, 2004). However, a perusal of the perfor-
mances of individual patients shows that left spatial
neglect may affect differently bisection deviations for
words and lines. In particular, patient DF exhibits a larger
rightward bias with words, as compared with lines, as
patients MP, GP, and MA. Conversely, in patient MV, the
rightward bias is greater with lines. The different impact
of spatial neglect on word and line bisection is supported
by the significant correlations, in control participants, of
the bisection errors for different lengths of the same
stimulus type (words, lines), but not between the two
different types of stimuli (words vs. lines). These findings
suggest that the processes involved in word and line
bisection are likely to be, at least in part, independent (see
also Arduino et al. 2010). At first, there is a difference
between lines and strings emerging early on in a lower-
level processing stage: Lines and words differ perceptu-
ally, being composed by continuous (lines) versus discrete
(letter strings, words) elements. In line with this view,
healthy participants show comparable deviations in the
bisection of both orthographic and symbolic strings (Ar-
duino et al. 2010). Although the bisection task explicitly
Exp Brain Res (2014) 232:133–146 141
123
requires a global processing of stimulus extent, in the case
of discrete strings, a processing of the local features may
be involved (see Gallace et al. 2008).
When focusing on the group of controls matched by age
with the patients, they do not show pseudoneglect, being
accurate with both lines and words. These results are in line
with a reduced pseudoneglect exhibited by elder partici-
pants in line bisection (see Jewell and McCourt 2000, for
review). Age may explain the lack of a left deviation even
for words, since the sample studied by Fischer (1996,
2004)—who reported a leftward bisection bias for words in
healthy participants—is younger than the one enrolled in
the present study. The reduction in the leftward deviation
could be interpreted in light of the hypothesis of a dis-
proportionate aging of the right hemisphere compared the
left one (Dolcos et al. 2002; Schmitz and Peigneux 2011).
Furthermore, right-brain-damaged N- patients exhibit a
rightward deviation for long lines, being accurate with all
the other types of stimuli, and this is in accordance with a
right-hemispheric involvement in the bisection task. Con-
versely, N? patients exhibit rightward deviations for lines
and words (the last almost significant), while they are
accurate with short stimuli.
A number of studies have investigated visuo-spatial
processing of verbal material with different results. In a
task requiring participants to circle the central letter of very
long character and symbol strings, as compared with line
bisection, neurologically unimpaired participants exhibit a
rightward deviation, which, in right-brain-damaged
patients with left neglect, is disproportionate (Lee et al.
2004). As compared with solid lines, greater demands on
local processing, left-hemisphere-supported, attentional
resources (Martin 1979) may be posed by the task of
bisecting strings of characters, and, more generally, strings
of discrete items. This may result in a task-induced left-
hemispheric activation, which in turn may bring about in
unimpaired participants a rightward bias, and exacerbate
the pathological rightward deviation made by right-brain-
damaged patients with left spatial neglect. Similarly, neu-
rologically unimpaired participants may show a rightward
deviation in bisecting long letter strings in which no word
is inserted, or in which a word (neutral, emotional) is
placed in the right or in the left hand side of the letter string
(Mohr and Leonards 2007). These findings argue for a role
of left-hemisphere-mediated semantic verbal processing
(Bowers and Heilman 1980) in letter and line bisection. In
the present study, as in Fischer (1996, 2000, 2004), the type
of stimuli—i.e., single words—could have activated a
reading strategy (from left to right in both English and
Italian language), once again mediated by the left hemi-
sphere and responsible of the leftward shifting of attention
and of the consequent bisection bias. As already discussed,
the differences with Fischer’s studies could be explained
by the age of the samples enrolled. The activation of a
reading strategy may be due to various factors, such as
stimulus readability, stimulus length, and the type of task
required. Fischer reported a leftward bisection error also
for pronounceable pseudowords and letter strings of com-
parable length to real words (Fischer 1996, 2000, 2004),
but not when vowels are replaced by x’s (Fischer 1996).
Furthermore, the stimuli used by Lee et al. (2004) and
Mohr and Leonards (2007) are very long (45–48 letters)
with respect to ones used in Fischer’s (1996, 2000, 2004)
and in the present study: The length of the stimuli would
prevent the processing of the letter strings as words, thus
not activating the reading strategy. Finally, the type of task
required by Lee et al. (2004) is to identify the target closest
to the mid-point, combining the demands of length judg-
ment with the visual search required in target cancellation.
As stated by the authors, this would require additional local
feature analyses mediated by the left hemisphere, in addi-
tion to global attention requested in mid-point judgment.
More in general, the double dissociation found in the
present study suggests that the processes involved in word
and line bisection are likely to be, at least in part, inde-
pendent: Other than the linguistic mechanism supported by
a reading strategy, a difference between continuous and
discrete material could be crucial (see also Arduino et al.
2010).
Experiment II assessed the impact of linguistic infor-
mation on word bisection in right-brain-damaged patients
with and without visuo-spatial neglect and control par-
ticipants. A reduced rightward bias when bisecting words
containing those final sequences characterizing irregu-
larly stressed stimuli (namely, with stress on the ante-
penultimate syllable) was found, at least for short words,
in the three groups of participants, with the different
types of words correlating within each group. The
overall lack of differences among groups may possibly
reflect the short (55 mm) length of the stimuli used.
There is wide evidence that the magnitude of the
patients’ bisection error is modulated by stimulus length,
with larger rightward errors with longer lines (see, e.g.,
Vallar et al. 2000 and references therein). In fact, the
mean length of both types of words (55.2 mm) is
broadly comparable to the mean length of the short
(44.6 mm) stimuli used in Experiment I, in which group
differences emerge only with longer words. Nevertheless,
patient GP, who exhibits left spatial neglect with both
types of stimuli, as compared to control participants,
shows a minor rightward deviation with antepenultimate
compared to penultimate final sequence words, with a
directional pattern similar to that of patients without
neglect and control participants. Orthographic and pho-
nological information present in the right hand side of
the stimulus appears to be able to induce a leftward bias.
142 Exp Brain Res (2014) 232:133–146
123
In conclusion, the present study provides evidence from
right-brain-damaged patients with left spatial neglect that
the processing of the lateral extent of line and word stimuli
is supported by at least partially independent processes,
which can be differentially affected by brain damage, and
that word bisection is influenced by lexical variables. More
generally, the processes which support the explicit esti-
mation of the lateral extent of linguistic material through
the setting of the mid-point of a horizontal letter string
(admittedly, a laboratory task, whose role in ecological
linguistic and visuo-spatial performances is not definite so
far), appear –as suggested by the double dissociation found
in individual patients between disproportionate rightward
deviations in word and line bisection– to rely on visuo-
spatial components specific for written language repre-
sentations. These, in turn, modulate bisection performance,
as shown by the results of Experiment II. These conclu-
sions are in line with the established dissociation between
visuo-spatial neglect (as indexed by cancellation and line
bisection tasks Bisiach and Vallar 2000, for review) and
neglect dyslexia (Vallar et al. 2010, for review), and extend
it to the computation of extent, as assessed by bisection of
different materials (line vs. letter strings). The present
pattern of double dissociations suggests that at least partly
different processes contribute to bisection performance of
letter strings and lines, which may be differentially affected
by right brain damage, bringing about selective patterns of
left spatial neglect.
Acknowledgments This study was performed in partial fulfillment
of the PhD program of L. V.. G. V. was supported in part by FAR
Grants from the University of Milano-Bicocca, and by Ricerca Cor-
rente Grants from the IRCCS Istituto Auxologico Italiano.
Appendix
Word sets of Experiment I
5-letter-long: tasca, posta, gesto, monte, spesa, vetro, disco,
poeta, fiore, borsa, cesto, perla, nuora, spiga, tarlo, mensa,
avena, fungo, amaca, talpa.
10-letter-long: conferenza, equilibrio, patrimonio, mag-
istrato tecnologia, entusiasmo, inflazione, dimensione,
contributo, superficie, parsimonia, pneumatico, mascalz-
one, crepuscolo, camaleonte, partigiano, didascalia, pro-
boscide, rimprovero, coriandolo.
12/13-letter-long: distribuzione, proprietario, informaz-
ione, testimonianza, disperazione, comunicazione, circo-
lazione, imprenditore, parlamentare, responsabile,
mobilitazione, verniciatura, prestigiatore, centralinista,
destinatario, registratore, razionalismo, orfanotrofio, trep-
idazione, comunicatore.
Experiment I: list of words, number of letters (N) and lengths of
words and comparable lines expressed in millimeter (L)
Word N L
1 fiore 5 34
2 tasca 5 43
3 poeta 5 45
4 posta 5 44
5 vetro 5 41
6 monte 5 51
7 disco 5 43
8 borsa 5 45
9 spesa 5 49
10 gesto 5 45
11 spiga 5 44
12 fungo 5 45
13 avena 5 50
14 amaca 5 55
15 Tarlo 5 35
16 talpa 5 38
17 perla 5 40
18 cesto 5 44
19 nuora 5 46
20 mensa 5 55
21 tecnologia 10 84
22 inflazione 10 78
23 contributo 10 82
24 dimensione 10 96
25 entusiasmo 10 96
26 patrimonio 10 87
27 equilibrio 10 75
28 conferenza 10 92
29 superficie 10 80
30 magistrato 10 87
31 camaleonte 10 97
32 mascalzone 10 100
33 didascalia 10 83
34 crepuscolo 10 91
35 parsimonia 10 91
36 partigiano 10 82
37 pneumatico 10 96
38 proboscide 10 91
39 coriandolo 10 86
40 rimprovero 10 89
41 disperazione 12 107
42 testimonianza 13 115
43 imprenditore 12 104
44 distribuzione 13 105
45 circolazione 12 99
46 parlamentare 12 110
47 proprietario 12 95
Exp Brain Res (2014) 232:133–146 143
123
Word sets from Experiment II
Penultimate final sequence words: alloro, ardita, canora,
castoro, decoro, dimora, eremita, fallita, malora, papiro,
parassita, ristoro, salita, sonoro, traforo, acrobata, angora,
bibita, canfora, cernita, decrepita, forfora, fosforo, logoro,
onnivoro, pecora, porpora, satiro, tacita, tortora.
Antepenultimate final sequence words: atomica, bambola,
bussola, fertile, fossile, muscolo, organica, ostacolo, pas-
colo, pugile, rettile, sogliola, tattile, tessile, tipica, badile,
barile, capriola, cazzuola, fienile, fucile, mollica, ortica,
ostile, pignolo, pistola, sedile, tritolo, usignolo, vescica.
Experiment II: list of words, stressed final sequence (StrSeq): pen-
ultimate (p) versus antepenultimate (a); lengths of words and com-
parable lines expressed in millimeter (L)
Word StrSeq L
1 alloro p 45
2 ardita p 45
3 canora p 56
4 castoro p 61
5 decoro p 57
6 dimora p 56
7 eremita p 61
8 fallita p 41
9 malora p 55
10 papiro p 51
11 parassita p 74
12 ristoro p 51
13 salita p 42
14 sonoro p 57
Word StrSeq L
15 traforo p 53
16 acrobata p 72
17 angora p 57
18 bibita p 43
19 canfora p 61
20 cernita p 55
21 decrepita p 76
22 forfora p 52
23 fosforo p 56
24 logoro p 51
25 onnivoro p 72
26 pecora p 55
27 porpora p 63
28 satiro p 45
29 tacita p 42
30 tortora p 52
31 atomica a 65
32 bambola a 70
33 bussola a 63
34 fertile a 44
35 fossile a 52
36 muscolo a 69
37 organica a 71
38 ostacolo a 69
39 pascolo a 63
40 pugile a 49
41 rettile a 45
42 sogliola a 62
43 tattile a 43
44 tessile a 51
45 tipica a 42
46 badile a 49
47 barile a 44
48 capriola a 65
49 cazzuola a 73
50 fienile a 47
51 fucile a 42
52 mollica a 56
53 ortica a 45
54 ostile a 43
55 pignolo a 59
56 pistola a 52
57 sedile a 48
58 tritolo a 44
59 usignolo a 69
60 vescica a 62
Word N L
48 comunicazione 13 126
49 informazione 12 107
50 responsabile 12 106
51 trepidazione 12 101
52 razionalismo 12 105
53 comunicatore 12 113
54 centralinista 13 100
55 prestigiatore 13 103
56 verniciatura 12 97
57 destinatario 12 97
58 orfanotrofio 12 95
59 registratore 12 94
60 mobilitazione 13 109
144 Exp Brain Res (2014) 232:133–146
123
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