European Psychiatry 20 (2005) 503–509
http://france.elsevier.com/direct/EURPSY/
Original article
Reliability of the Spanish version of the Composite Scale of Morningness
A. Adan a,*, H. Caci b, G. Prat a
a
Department of Psychiatry and Clinical Psychobiology, School of Psychology, University of Barcelona, Passeig Vall d’Hebrón 171,
08035 Barcelona, Spain
b
Service de pédiatrie, hôpital Archet-2, CHU de Nice, 151, route de Saint-Antoine-de-Ginestière, 06202 Nice cedex 3, France
Received 19 September 2004; accepted 13 January 2005
Available online 25 March 2005
Abstract
Aim. – The aim of this study was to examine the reliability of the Spanish version of Composite Scale of Morningness (CSM) and its ability
to measure the circadian typology.
Subjects and methods. – Voluntary and unpaid psychology students (N = 391; 132 men and 259 women), aged between 17 and 33,
completed the questionnaire between the months of September and December.
Results. – The total score was independent of age and gender, with a close to normal distribution and a non-significant negative skewness.
The internal consistency was high (Cronbach’s ␣ = 0.87) and factor analysis extracted three factors labeled Time of Retiring (items 2 and 7),
Activity Planning (items 8, 9, and 13) and Morning Affect (items 3–6, and 10–12). With the 10th and 90th percentiles as cut-off scores, scorers
below 22 (N = 40; 10.2%) are classified as evening-types and scorers above 39 as morning-types (N = 28; 7.2%).
Conclusion. – The Spanish questionnaire shares most of the good psychometric properties of other versions of the CSM, and thus can be
used for Spanish-speaking student samples. Nevertheless, further studies of normative data in workers and aged subjects are needed in order
to validate CSM.
© 2005 Elsevier SAS. All rights reserved.
Keywords: Chronobiology; Circadian rhythms; Chronotype; Morningness; Eveningness; Questionnaire; Gender differences
1. Introduction
A pervasive characteristic of mammals is the existence of
rhythmic changes that can be observed on several levels of
organization from basic cellular phenomena to complex
behaviors. The endogenous mechanisms, also called pacemakers, are adjusted (i.e. synchronized) to environmental
cycles, chiefly the light–dark cycle [16,23,34]. The morningness–eveningness dimension is a continuum on which individuals can be arranged from the morning-type or “lark” to
the evening-type or “owl”, with a larger intermediate group.
It is associated with interindividual differences in rhythmic
expression, such as academic, professional and sport performance [12,23,41], and is also related to personality traits and
to psychopathologic risk factors at adolescence and adulthood [10–12,17,23].
Circadian typology is assessed by means of self-rating
questionnaires; the first constructed and the most widely used
* Corresponding author.
E-mail address: aadan@ub.edu (A. Adan).
0924-9338/$ - see front matter © 2005 Elsevier SAS. All rights reserved.
doi:10.1016/j.eurpsy.2005.01.003
is the Morningness–Eveningness Questionnaire (MEQ) [22].
Some of the criticisms addressed to the MEQ are that the
total score may not be appropriate to measure a multidimensional construct [31], and that small subsets of items may
convey most of the total variance of the measure [1,15]. Two
other questionnaires have been proposed about which similar
criticisms have been raised: the Circadian Type Questionnaire (CTQ) [21], the Diurnal Type Scale (DTS) [19,39]. With
this in mind Smith et al. [36] developed a new questionnaire
they called the Composite Scale of Morningness (CSM) which
is composed by the ‘best’ items of the MEQ (nine items) and
the CTQ (four items). Several studies have demonstrated the
good CSM test–retest reliability [9,20], and an adequate external validity when considering different variables. The total
score ranges from 13 (extreme evening-type) to 55 (extreme
morning-type). The authors arbitrarily proposed to retain the
10th and 90th percentiles as cut-off scores to classify the subjects into one of the above three categories, which correspond to the scores of 22 and 44, respectively, in their sample.
On the other hand, Alzani and Natale [4] proposed a fixed
504
A. Adan et al. / European Psychiatry 20 (2005) 503–509
cut-off approach dividing the theoretical range of the total
score (i.e. 55 – 13 = 42) in three equal parts: 13 + (55–
13)/3 = 27 and 27 + (55 – 13)/3 = 41. Unfortunately, international research has established that the centiles do vary across
samples [35], e.g. 27 and 44, respectively, in Australia [20],
or 27 and 41, respectively, in Italy [30], or 30 and 45, respectively, in France [9]. Consequently the blind conversion of
the total score into a typology using whatever cut-off scores
implies that one ignores this critical point. One solution may
be to establish normalized cut-off scores with regard to nationality, age and gender before using the questionnaire in smaller
groups or individually.
Many studies have pointed out that age and gender both
influence morningness. In adults the trend toward morningness increases with age [13,18,38,43], and women show a
greater trend toward morningness than men in their rhythm
expression [3,32]. But the relation between gender and morningness scores remains controversial: some researchers did
not obtain significant differences between men and women
[2,8,15,20] while others did using larger samples [3]. Moreover, like what is reported for some other personality traits,
the relationship between age and morningness may not be
linear across the age span [3,14,29]. It could be of interest to
[25,31,42] analyze more accurately the potential differences
between men and women in morningness–eveningness scores
on the CSM.
In the last decade, the use of CSM has progressively
increased as the questionnaire was translated into several languages [4,8,30,33]. Regarding the structure of CSM, a threefactor solution was found in three independent Englishspeaking samples. The factors were called Morningness/
Effort, Evening, and Morning Affect, this latter being the more
robust factor [6,36]. The Thaï version also obtained three components with some differences from the English version [33].
Although the authors of the Italian version retained a onefactor solution in both a student and a shiftworker samples,
they also provided a plot of the eigenvalues suggesting the
appropriateness of a three-factor solution [4]. In France, a
one-factor solution was provisionally accepted [8] but a threefactor solution emerged later [9,10]. A transcultural work with
large samples (Australia, France, Italy, Spain, and Thailand)
also obtained a three-factor solution in all five countries [7].
The aim of this study is to examine the reliability of the
Spanish version of the CSM in student subjects, including
the analysis of the factor structure, and to take into account
the potential gender differences in the structure and the raw
scores. The typology will be determined following previous
works [30,36] to establish the optimal categorization system.
2. Materials and methods
2.1. Subjects
Participants were 391 undergraduate students (132 men
and 259 women), aged between 17 and 33 (19.94 ±
2.22 years). All were voluntary, anonymous and unpaid. As
expected in student samples, the Shapiro–Wilk tests indicate
that age is positively albeit slightly skewed in total sample
(W = 0.883, P < 0.001) and for both genders (men: W = 0.870,
P < 0.001; women: W = 0.892, P < 0.001). In fact, 65.7% of
the subjects were younger than 21. Men were about 9 months
older than women (Z = 2.71, P < 0.007).
2.2. Measures and procedure
The CSM was translated into Spanish and then back translated into English by two bilingual English speakers to ensure
translation quality (see Appendix 1 for the Spanish version).
Following we briefly described each one of the 13 items
included in the CSM: 1 (At what time would you get up?), 2
(At what time would you go to bed?), 3 (How easy do you
find getting up in the morning?), 4 (How alert do you feel
during the first half hour after awakening?), 5 (How tired do
you feel during the first half hour after awakening?), 6 (Physical exercise at early morning), 7 (At what time in the evening
do you feel tired and in need of sleep?), 8 (Hour of peak for
mental performance), 9 (Self-assessment of circadian typology), 10 (When would you prefer to rise?), 11 (If you were
always to rise at 6:00 a.m. what were would you be like?), 12
(How long a time does it take before you “recover your
senses” after rising?), and 13 (To what extent is an individual
oriented toward morning or evening).
Subjects completed the CSM in a morning session of a
Psychology course at the University of Barcelona between
the months of September and December. The CSM was
administered to 400 students (a sample-size adequate to the
aim of the study) ranged into five class-group. Before the
administration of the CSM, students received a brief introduction about the nature of research, ethical requirements for
confidentiality and voluntary participation. No informed consent was required. The response rate was close to 100% of
the subjects present in each class and we have information
about all the items since we control missing values.
2.3. Statistical analysis
Scores are expressed as mean, standard deviation (S.D.)
and range, and their distribution shapes were assessed for normality with the Shapiro–Wilk test. The reliability of the scores
was estimated by the unstandardized unit-weighted Cronbach’s a coefficient. The CSM total score was submitted to
an ANCOVA with gender as factor and age as covariate. Gender differences on item scores were tested by the two-sample
Wilcoxon rank-sum test since the item responses are on an
ordinal scale.
We explored the structure underlying the 13 items of the
CSM by exploratory factor analysis. Because the item scores
are not normal by nature, we used the Weighted Least Squares
estimator with Mean- and Variance-adjustment (WLSMV)
[26]. The number of factors to extract was determined by Cattell’s scree test and an oblique PROMAX rotation was applied.
A. Adan et al. / European Psychiatry 20 (2005) 503–509
The solution was considered as satisfactory if the Standardized Root Mean Residual (SRMR) index was lower than
0.050. The similarity of each factor between genders was
assessed by the Tucker’s congruence coefficient, which can
be used with oblique solutions. Previous work on factor similarity with large real data samples has showed that coefficients greater than 0.800 indicate good congruence between
factors [5]. Analyses were run on Stata 7 [37] and Mplus 2.02
[27], and statistical tests were two-way with a type-I error set
at 5%.
3. Results
3.1. Descriptive statistics and reliability
The mean score for CSM was 30.74 (S.D. = 6.54; range:
14–48) in total sample, 30.23 (S.D. = 6.74; range: 16–48) in
men and 31.00 (S.D. = 6.43; range: 14–46) in women. The
CSM score had a marginally significant Shapiro–Wilk test in
the total sample (W = 0.993; P = 0.047), while it is normally
distributed in both genders as indicated by non-significant
(ns) Shapiro–Wilk tests (men: W = 0.994, P = 0.256; women:
W = 0.985, P = 0.165). The distributions shapes are similar
between genders (Kolmogorov–Smirnov D = 0.084; ns), and
not significantly skewed to morningness were never obtained
(total sample: skewness = –0.202, P = 0.100; men: skewness = –0.096, P = 0.636; women: skewness = –0.253; P >
0.09).
There was no effect on the CSM total score of gender
(F(1,387) = 1.26; ns) and age (F(1,387) = 1.63; ns) nor gender x age interaction (F(1,387) = 0.86; ns). Spearman rankorder coefficient between age and CSM score did not show
any significant correlation when considering all the subjects
(q = 0.049), only men (q = –0.008) or women (q = 0.088).
The reliability of the entire scale is excellent in total sample
(␣ = 0.877) and similar between genders (men: ␣ = 0.889;
women: ␣ = 0.985). The values of the 10th and 90th percentiles in our sample were, respectively, 21 and 39 in the total
sample, 20 and 39 in men, and 22 and 39 in women. These
values are close to those reported in the original study [36]
but the resulting categorization would be slightly biased
toward eveningness: 40 evening-types (10.2%; 18 men and
22 women), 323 neither-types (82.6%; 150 men and
218 women), and 28 morning-types (7.2%; nine men and
19 women). There is no difference between genders in the
assignment to these three groups (v2(2) = 2.52; ns). Now considering the fixed cut-offs of 27 and 41, the resulting categorization shows a greater bias toward eveningness:
113 evening-types (28.9%; 39 men and 74 women), 261 neither-types (66.8%; 85 men and 176 women), and 17 morningtypes (4.35%; eight men and nine women). There is no difference between genders in the assignment to these three
groups (v2(2) = 1.54; ns). Therefore, it would seem more
adequate for Spanish student samples to maintain the
percentile-based approach. However, in studies aimed at
selecting subjects from the different categories less restrictive cut-off scores should be used, such as the percentiles 20th
for the evening-type (cut-off = 25; total sample: 91 (23.3%);
35 men and 56 women) and 80th for the morning-type (cutoff = 37; total sample: 61 (15.6%); 19 men and 42 women).
Then again there is no difference between genders in the
assignment to these three groups (v(2) = 1.22; ns).
Table 1 shows the mean scores of all the 13 items of the
CSM with regard to gender (high scores indicating a trend
toward morningness), along with the rank-order correlation
between an item and the sum of the other twelve items. As in
many previous studies in other languages, the lowest correlation appears with item 7 and the highest with item 9, which
is a “validity check item” for the morningness–eveningness
dimension. Women have higher scores than men on item 2
(Z = –3.02; P < 0.003), 7 (Z = –1.97; P = 0.049) and 9 (Z = –
2.83; P < 0.005), whereas men have a higher score on item
1 only (Z = 2.88; P = 0.004).
3.2. Factor analysis
With respect to Cattell’s scree test, we extracted three factors from the 13 items of CSM in the total sample and in both
Table 1
Mean score ± S.D. and item-corrected total rank-order correlation coefficients for all 13 items of the CSM in the total sample and according to gender
Item
1
2
3
4
5
6
7
8
9
10
11
12
13
Total sample
(N = 391)
2.39 ± 0.78
2.42 ± 0.75
2.36 ± 0.76
2.26 ± 0.73
2.49 ± 0.66
2.06 ± 0.72
2.37 ± 0.75
2.94 ± 0.95
2.25 ± 0.78
1.79 ± 0.67
2.15 ± 0.84
2.90 ± 0.85
2.37 ± 0.97
Items scores
Men
(N = 132)
2.55 ± 0.80
2.27 ± 0.77
2.34 ± 0.78
2.20 ± 0.73
2.55 ± 0.67
2.05 ± 0.75
2.26 ± 0.78
2.92 ± 0.88
2.08 ± 0.79
1.81 ± 0.71
2.08 ± 0.83
2.81 ± 0.82
2.32 ± 0.96
Women
(N = 259)
2.31 ± 0.76
2.50 ± 0.73
2.38 ± 0.75
2.30 ± 0.74
2.45 ± 0.65
2.06 ± 0.71
2.42 ± 0.73
2.95 ± 0.98
2.34 ± 0.77
1.78 ± 0.65
2.18 ± 0.84
2.94 ± 0.87
2.40 ± 0.98
505
Total sample
(N = 391)
0.571
0.482
0.630
0.534
0.534
0.491
0.415
0.499
0.750
0.531
0.537
0.546
0.649
Item-corrected total rank order correlation
Women
Men
(N = 259)
(N = 132)
0.540
0.622
0.562
0.446
0.602
0.647
0.555
0.518
0.554
0.533
0.552
0.460
0.465
0.385
0.571
0.460
0.780
0.738
0.501
0.552
0.498
0.554
0.538
0.550
0.693
0.623
506
A. Adan et al. / European Psychiatry 20 (2005) 503–509
Table 2
Eigenvalues of the correlation matrices
Total sample
(N = 391)
6.154
1.600
0.943
0.921
0.610
0.539
0.494
0.403
0.344
0.315
Men
(N = 132)
6.479
1.611
0.969
0.872
0.710
0.611
0.544
0.319
0.258
0.246
The oblique solutions were assessed for similarity between
genders using Tucker’s coefficient of congruence. All the coefficients for heterogeneous pairs are very low, ranging from
–0.111 (F1–F3 pair) to + 0.473 (F1–F2 pair). The coefficients for homologous pairs were highest for the Morning
Affect factor (F3–F3 = 0.937), and close to the threshold of
0.800 for the Time of Rising (F1–F1 = 0.795) and Activity
Planning (F2–F2 = 0.778).
Women
(N = 259)
6.083
1.675
0.966
0.888
0.573
0.517
0.490
0.457
0.350
0.313
4. Discussion
gender groups (Table 2). With regard to the SRMR, the
oblique three-factor solutions are good in the total sample
and in the women group (SRMR < 0.05) but less satisfactory
in the men group (Table 3). We labeled the first factor Time of
Retiring, composed by items 2 and 7. The second factor,
named Activity Planning, is composed by items 8, 9, and 13.
The third factor, labeled Morning Affect, counts seven items
and previously appeared in several studies independently of
the language. This latter factor is composed by items 3, 4, 5,
6, 10, 11, and 12. In women, item 11 was allocated on the
Morning Affect factor, according to its primary loading of
0.493, the low secondary loadings and its salient loading in
men. Although item 1 loads on the Time of Retiring factor in
the men group only, we think it should not be discarded from
the CSM as it reports relevant informations on sleep preference. Items 1 and 10 both refer to the time of rising in the
morning. Thus if we accept that morningness is independent
from the duration of sleep then it is not surprising that both
these items load positively on the Time of Retiring factor
(which may be renamed Sleep Planning). Anyway, we do not
have any explanation for the low loadings of items 1 and 10 in
women.
Psychometric properties reported in the present work are
similar to those reported in other countries and languages
[4,8,33,36], suggesting the Spanish version of the questionnaire is effective and reliable. Our sample was larger than
those used in standardizing studies realized in these other
countries but this does not mean that it was representative of
the Spanish student population. Nevertheless, our work is the
first step to use this scale in circadian typology research in
Spain and in Spanish-speaking countries. There is now a need
to obtain normative data in a larger sample of subjects and to
validate the questionnaire with biological and behavioral
external parameters.
The CSM total score was normally distributed in both gender groups with a marginally significant Shapiro–Wilk test in
the entire sample, and a non-significant skewness in all cases.
This result allows us to use the percentile-based method to
categorize the subjects. With regard of the MEQ, it is admitted that 15–20% of the subjects are classified in each of the
extreme categories (morning- and evening-type) [2,14,28,
29,38]. The fixed cut-off scores approach is biased toward
eveningness and may imply a difficulty in research studies if
CSM was used to categorize subjects into extreme typologies [17,41]. Spanish subjects are classified as evening-type
(scores lower or equal to 21), as neither-type (scores between
Table 3
Exploratory factor analysis (WLSMV estimator) of the CSM for the total sample and each gender group, with factor intercorrelations and Square-Root Mean
Residual (SRMR). Loadings equal or greater than 0.500 in absolute value are in bold
Item 1
Item 2
Item 3
Item 4
Item 5
Item 6
Item 7
Item 8
Item 9
Item 10
Item 11
Item 12
Item 13
F2
F3
SRMR
0.322
0.875
–0.146
–0.056
–0.152
0.113
0.939
–0.075
0.203
0.218
0.009
0.039
0.040
0.537
0.447
0.043
All sample
(N = 391)
0.105
0.012
0.161
–0.100
0.037
–0.055
0.052
0.704
0.664
0.018
0.094
0.108
0.777
1.000
0.622
0.405
0.006
0.778
0.845
0.796
0.632
–0.154
0.055
0.164
0.513
0.606
0.580
0.070
—
1.000
0.655
0.750
–0.110
–0.125
–0.085
0.264
0.893
0.065
0.158
0.628
0.040
0.041
0.091
0.323
0.474
0.063
Men
(N = 132)
–0.013
0.400
0.170
0.056
0.069
0.018
0.375
0.532
0.540
–0.213
0.050
0.166
0.644
1.000
0.374
0.218
–0.104
0.763
0.855
0.767
0.502
–0.293
0.300
0.442
0.363
0.637
0.555
0.343
—
1.000
0.177
0.964
–0.124
0.074
–0.019
0.004
0.735
–0.122
0.172
–0.001
–0.066
0.088
0.038
0.488
0.294
0.039
Women
(N = 259)
0.343
–0.043
0.213
–0.200
–0.033
0.075
0.209
0.712
0.746
0.276
0.284
0.073
0.773
1.000
0.619
0.371
0.071
0.736
0.853
0.796
0.580
–0.132
–0.005
0.101
0.453
0.493
0.607
0.018
—
1.000
A. Adan et al. / European Psychiatry 20 (2005) 503–509
22 and 39) and as morning-type (scores greater or equal to
40). Finally, research studies should apply the looser criteria
(such as the percentiles 20 and 80) to select moderate eveningtype and morning-type, respectively. That is, scores lower or
equal to 25 correspond to the evening-type and, scores equal
or greater to 37 correspond to the morning-type subjects.
It could be interesting to study other population groups,
such as workers and especially those doing shift work. A previous work has obtained similar descriptive data and cut-off
scores for CSM in shift workers [4]. In this study we only
selected students because this group of subjects had fewer
constraints to social synchronizers [24] (i.e. work schedule)
and can express with greater liberty their rhythmic preference. This is the reason why students are more frequently
included in circadian typology research. As a corollary, we
were not able to explore the well known relationship between
scores of morningness–eveningness and age since our age
interval was smaller [13,18,23,38,40]. However, a clear morning orientation seems to appear by age 50 with associated
sleep problems, sensitivity to jet-lag, and less adaptation to
changes in hourly schedule and work shifts [32].
The analysis of factor structure of the CSM suggested to
obliquely rotate a three-factor solution, namely: Time of Rising (items 2 and 7), Activity Planning (items 8, 9 and 13),
and Morning Affect (items 3–6 and 10–12). This factor solution is similar to that obtained in previous studies [6,7,10]
with the Morning Affect factor being to the most robust. The
factor structure was also similar between genders, with a
greater congruency for the Morning Affect factor and a close
to satisfactory congruency for the other two factors. This factor structure has profound theoretical and practical implications that future studies should take into account in students
and in other population groups. The factor Time of Rising is
more influenced by environmental constraints and could be
less endogenously determined. The Activity Planning factor
involves mainly the self-perception of circadian typology.
And, the Morning Affect factor could be a short CSM scale
useful when a rapid and accurate measure of circadian endogenous organization is needed.
In all analyses men and women were considered separately. The differences between genders appear mainly when
we explore the factor structure of questionnaire, and descriptive data on the entire scale did not show any significant difference between genders. This latter result is not in line with
previous studies that reported a gender effect on the morningness–eveningness scores using larger samples [3,14,28,29].
This difference is not very large, however, casting doubt on
the possibility to reveal such an effect using questionnaires
only whereas its genetic basis [40] and its relationship with
the different functionality of the women endocrine system
have been reported [28]. Obviously, our sample was large
enough to establish the psychometric properties of the Spanish version of the CSM but lacked in power to detect a small
gender effect.
507
5. Conclusion
The CSM is a psychometrically sound instrument in its
Spanish version also. The factor structure was constituted by
three factors: Time of Retiring (items 2 and 7), Activity Planning (items 8, 9 and 13), and Morning Affect (items 3–6, and
10–12). Considering the more restrictive criteria of the cutoff (percentiles 10 and 90), evening-type subjects have a score
of 21 or less, and morning-type subjects have a score of at
least 40. We did not find any gender effect on item scores,
total score and distribution shape of the total score. There
were some discrepancies in the three-factor solution between
genders, especially regarding the Time of Retiring factor.
Future works should be carried out in order to obtain normative data and involving other population groups such as shift
workers and subjects with a wider age range, as well as using
external criteria, in order to validate the CSM in Spanishspeaking subjects.
Appendix 1
Spanish version of the Composite Scale of Morningness
(CSM)
Escala compuesta de matutinidad
Instrucciones. Por favor, lea atentamente cada pregunta
antes de responder. Conteste a todas las preguntas en el orden
presentado y sin revisar las respuestas precedentes. Su información permanecerá en secreto, intente por lo tanto responder
lo más sinceramente posible. Las preguntas prevén una serie
de respuestas, escoja sólo la que mejor le describe. Gracias
por su colaboración.
1. Considerando solamente su ritmo personal de “sentirse
en forma”, ¿a qué hora se levantaría si fuese completamente
libre para planificar su jornada ?
5:00–6:30 a.m.
6:30–7:45 a.m.
7:45–9:45 a.m.
9:45–11:00 a.m.
11:00–12:00 (mediodía)
2. Considerando solamente su ritmo personal de “sentirse
en forma”, ¿a qué hora se iría a la cama si fuese completamente libre para planificar su jornada ?
20:00–21:00 p.m.
21:00–22:15 p.m.
22:15–00:30 a.m.
00:30–1:45 a.m.
1:45–3:00 a.m.
3. En circunstancias normales, ¿en qué medida le resulta
fácil levantarse por la mañana ?
nada fácil
no demasiado fácil
bastante fácil
508
A. Adan et al. / European Psychiatry 20 (2005) 503–509
muy fácil
4. ¿Cuán despabilado se encuentra durante la primera
media hora después de haberse despertado ?
nada despabilado
un poco despabilado
bastante despabilado
muy despabilado
5. Durante la primera media hora de haberse despertado
se encuentra usted...
muy cansado
bastante cansado
bastante descansado
muy descansado
6. Ha decidido practicar algún ejercicio físico. Un amigo
le sugiere que debería hacerlo durante une hora dos veces a la
semana y que la mejor hora es entre las 7:00 y las 8:00 de la
mañana. Considerando exclusivamente su ritmo de “sentirse
en forma”, ¿cómo se encontraría a esa hora ?
estaría en optima forma
estaría en buena forma
me resultaría difícil
me resultaría muy difícil
7. ¿A que hora se encuentra cansado/a por la noche y siente
la necesidad de dormir ?
20:00–21:00 p.m.
21:00–22:15 p.m.
22:15–00:30 a.m.
00:30–1:45 a.m.
1:45–3:00 a.m.
8. Usted debe hallarse en el momento de máximo rendimiento para realizar una prueba que le cansará mentalmente y que dura dos horas. Si es enteramente libre para planificar su jornada, ¿cuál de los siguientes periodos horarios
elegiría ?
8:00–10:00 a.m.
11:00 a.m.–13:00 p.m.
15:00–17:00 p.m.
19:00–21:00 p.m.
9. Suele hablarse de personas de tipo “matutino” y de tipo
“vespertino”. ¿A cuál de estos dos tipos cree pertenecer ?
claramente “matutino”
más “matutino” que “vespertino”
más “vespertino” que “matutino”
claramente “vespertino”
10. Suponiendo que realiza un trabajo de 8 horas al día y
que es totalmente libre de gestionar su tiempo, ¿cuándo preferiría levantarse ?
antes de las 6:00 a.m.
6:00–7:30 a.m.
7:30–8:30 a.m.
después de las 8:30 a.m.
11. Si tuviese que levantarse siempre a las 6:00 de la
mañana, ¿como lo valoraría ?
muy difícil y molesto
bastante difícil y molesto
un poco molesto pero no sería un problema
fácil y no molesto
12. ¿Cuánto tiempo transcurre normalmente por la mañana
para que se “despierte del todo” después de una noche de
sueño ?
0–10 minutos
11–20 minutos
21–40 minutos
más de 40 minutos
13. Indique cuál de las siguientes afirmaciones define mejor
su patrón de actividad.
marcadamente activo por la mañana (despierto por la
mañana y cansado por la tarde)
moderadamente activo por la mañana
moderadamente activo por la tarde
marcadamente activo por la tarde (cansado por la
mañana y despierto por la tarde)
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