UWA Research Publication
Milne, E., Greenop, K. R., Scott, R. J., Ashton, L. J., Cohn, R. J., de Klerk, N. H. and
Armstrong, B. K. (2013), Parental smoking and risk of childhood brain tumors. Int. J.
Cancer, 133: 253–259. doi: 10.1002/ijc.28004.
Copyright © 2012 UICC
This is the peer reviewed version of the following article: Milne, E., Greenop, K. R.,
Scott, R. J., Ashton, L. J., Cohn, R. J., de Klerk, N. H. and Armstrong, B. K. (2013),
Parental smoking and risk of childhood brain tumors. Int. J. Cancer, 133: 253–259. doi:
10.1002/ijc.28004, which has been published in final form at
http://dx.doi.org/10.1002/ijc.28004. This article may be used for non-commercial
purposes in accordance with Wiley Terms and Conditions for self-archiving.
This version was made available in the UWA Research Repository on 1 July 2014 in
compliance with the publisher’s policies on archiving in institutional repositories.
Use of the article is subject to copyright law.
SHORT REPORT
Parental smoking and risk of childhood brain tumours
Short title: Parental smoking and CBT
Authors: Elizabeth Milne1, Kathryn R.Greenop1, Rodney J. Scott2, 3, Lesley J. Ashton4,
Richard J. Cohn5, 6, Nicholas H. de Klerk1, Bruce K.Armstrong7.
1
Telethon Institute for Child Health Research, Centre for Child Health Research, University
of Western Australia, Perth, Western Australia, Australia.
2
Hunter Medical Research Institute, School of Biomedical Sciences, Faculty of Health,
University of Newcastle, New South Wales, Australia.
3
Hunter Area Pathology Service, HNEHealth, Newcastle, New South Wales, Australia.
4
Children’s Cancer Institute Australia for Medical Research, Lowy Cancer Research Centre,
University of New South Wales, Sydney, NSW, Australia.
5
Centre for Children's Cancer and Blood Disorders, Sydney Children's Hospital, Sydney,
Australia;
6
School of Women's and Children's Health, Faculty of Medicine, University of New South
Wales, NSW, Australia.
7
Sydney School of Public Health, University of Sydney, Sydney, New South Wales, Australia
Author for correspondence:
Dr Elizabeth Milne
Telethon Institute for Child Health Research
PO Box 855 West Perth, Western Australia 6872, Australia
Telephone: +61 08 9489 7756
Facsimile: +61 08 9489 7700
Email: lizm@ichr.uwa.edu.au
1
Keywords: children, central nervous system neoplasms, tobacco, smoking, pregnancy,
conception
Abbreviations: CBT: childhood brain tumors, OR: odds ratio, CI: confidence interval, CD:
collection district, IRSD: Index of relative socioeconomic disadvantage, RDD: random digit
dialling, PNET: primitive neuroectodermal tumor.
Current text word count: 2325
Novelty and impact of paper:
In our national study of childhood brain tumors, we used a novel method to measure parental
smoking. Parents were asked about annual smoking quantity, with recall anchored to
occupational and residential history to reduce bias. Overall, parents’ smoking was not related
to brain tumour risk, but the OR for maternal smoking during pregnancy was consistent with a
four-fold increase in risk among children aged under 2 years, suggesting a possible
association with early childhood tumours.
2
Abstract
= 245
Childhood brain tumors (CBT) are the leading cause of cancer death in children, yet their
etiology remains largely unknown. Tobacco smoke contains 61 known carcinogens and
increases the risk of several adult cancers. This study investigated associations between
parental smoking and risk of CBT in a population-based case-control study conducted
between 2005 and 2010. Cases were identified through all 10 Australian paediatric oncology
centres, controls via nationwide random-digit dialling, frequency matched to cases on age, sex
and state of residence. Parental smoking information was obtained for 302 cases and 941
controls through mailed questionnaires that requested average daily cigarette use in each
calendar year from age 15 to the child’s birth, linked to residential and occupational histories.
Data were analysed using unconditional logistic regression, adjusting for frequency matching
variables and potential confounders. Overall, parental smoking before or during pregnancy
showed no association with CBT risk. The odds ratios for maternal smoking before and
during pregnancy were 0.99 (95% CI: 0.70, 1.40) and 0.89 (95% CI: 0.61, 1.21) respectively,
and those for paternal smoking before and during pregnancy were 0.99 (95% CI: 0.71, 1.38)
and 1.04 (95% CI: 0.74, 1.46) respectively. In children under 24 months of age, the odds
ratios for maternal smoking preconception and during pregnancy were 5.06 (95% CI 1.3519.00) and 4.61 (95% CI: 1.08, 19.63), although these results were based on modest numbers.
Future studies should investigate the associations between maternal smoking and risk of CBT
by the child’s age of diagnosis.
3
Introduction
Childhood brain tumors (CBT) are the leading cause of cancer death in children, and apart
from a few genetic syndromes and ionising radiation, their etiology is largely unknown. A
range of environmental factors have been investigated as potential risk factors, but most of the
findings have been inconclusive.1
Tobacco smoke contains 61 known carcinogens and is considered to increase the risk of adult
cancers including lung, oro-pharyngeal, pancreatic and renal cancers.2 The results of previous
studies of maternal smoking and CBT risk have been inconsistent. While most early studies,
including a 1996 review3 and a 2002 meta-analysis,4 concluded there was no evidence of
associations with maternal smoking before pregnancy and during pregnancy, moderately
increased risks with smoking before5 pregnancy and during pregnancy6 have recently been
reported.. In addition, Schuz and co-workers reported positive associations between maternal
smoking during pregnancy and risk of ependymoma and medulloblastoma, but not
astrocytoma7 but other relatively recent studies have reported null results.8-10 Previous studies
of paternal smoking and risk of CBT have also produced inconsistent results; two studies
published after the review by Norman and colleagues3 reported positive associations,8,
11
while six reported no association.5, 7, 12-15
These inconsistent findings could be partly due to differences in study design and the way
parental smoking histories were obtained and quantified; and, perhaps to lack of investigation
of disease subtypes in some studies.4 Here we present results from our Australian casecontrol study, in which detailed smoking histories were obtained from both parents, and
associations within CBT subtypes were examined.
Methods
The Australian Study of Childhood Brain Tumours (Aus-CBT) was a national populationbased case-control study conducted between 2005 and 2010. The study design has been
described previously.16 Briefly, incident cases were identified through all 10 Australian
pediatric oncology centers where most CBTs are treated. Cases were eligible for inclusion if
they were resident in Australia and had a biological parent available with adequate English
skills to complete the questionnaires. Cases diagnosed in 2005 were recruited retrospectively,
while 2006-2010 cases were recruited as soon as possible after diagnosis. Controls were
recruited by national random digit dialing (RDD) between 2005 and 2010, and frequency
matched to cases by age (within 1 year), sex and state of residence in a ratio of approximately
4
3:1. The RDD method has been described in detail elsewhere.17 Aus-CBT was approved by
the Human Research Ethics Committees at all participating hospitals.
Questionnaires mailed to parents asked about demographic characteristics, medical histories,
engagement in activities involving potential exposure to carcinogens and diet. Parents were
asked to indicate the average number of cigarettes smoked per day (CPD) in each calendar
year from age 15 until the year after the index child’s birth along with their residential address
and occupation in each year. Smoking data were referenced to the child’s birth year so that
smoking during critical periods relating to the pregnancy could be determined. Smoking
during pregnancy was defined as smoking during the birth year (if the child was born in or
after May) or during the year before the birth year (if the child was born before May).
Preconception smoking was defined as smoking in the year before the birth (for births in or
after May) or in the year two years before the birth (for births before May). We also
investigated whether parental ever smoking, former smoking or pack-years of smoking were
associated with CBT risk. In addition to parent-reported measures of socio-economic status
(SES), each participant’s address was linked to an Australian Bureau of Statistics (ABS)
Census Collection District (CD). The ABS assigns each CD a score for its area-based Index
of Relative Socio-Economic Disadvantage (IRSD) after each quinquennial census
[http://www.ausstats.abs.gov.au/Ausstats/subscriber.nsf/0/D729075E079F9FDECA25741700
11B088/$File/20390_2006.pdf].
Statistical analysis
Unconditional logistic regression was used to estimate odds ratios (ORs) for the association
between parental smoking in specific time periods and risk of CBT. All analyses included the
frequency matching variables age, sex and State of residence, and variables that met the
classical definition of confounding; that is, they were associated with case/control status, and
with smoking among control parents. The variables included on this basis were ethnicity,
parental age, child’s year of birth, household income and maternal alcohol consumption (for
maternal smoking models). Interactions with child’s age and parental alcohol consumption
were tested by fitting interaction terms in the models. Subgroup analyses were undertaken by
CBT subtype where there were sufficient cases.
Results
We were notified of 794 CBT cases, of whom 64 were ineligible (36 with no Englishspeaking parent, 23 non-residents, five with no biological parent available). Of the 730
5
eligible cases, 568 (77.8%) were invited to take part by a physician, while a physician chose
not to invite the other 162 for medical or psychosocial reasons. Parents of 374 cases
consented (65.8% of invited, 51.2% of eligible). Information on smoking was available for
302 (85.1%) case mothers and 247 (68.5%) case fathers, while 29 families provided only
demographic information and 39 provided no data. Between 2005 and 2010, 3,624 families
eligible to be controls were identified by RDD, of whom 2,255 (62.2%) agreed to participate.
In accordance with our age and sex frequency-matching quotas, we recruited 1,467 of these
children to the study. Information on smoking was available for 941 control mothers (69.0%
of recruited) and 801 control fathers (58.8% of recruited), while 413 families provided only
demographic data and 104 families provided no data.
Demographic and other characteristics of cases and controls who provided at least some data
were similar, with some exceptions (Table 1). Controls were slightly more likely than cases
to be female, have a mother aged over 35 years and have European ethnicity. A higher
proportion of controls than cases were recruited in 2005-2006, as controls from our national
leukemia study were frequency matched to CBT cases diagnosed in those years. The use of
the 2005 and 2006 leukemia study controls also resulted in a higher percentage of controls
than cases born between 1998 and 2003. Thus, the child’s age and year of recruitment were
related.
Both cases and controls lived in more socially advantaged CDs than the Australian population
as a whole. The mean IRSD scores were 1025.3 for case CDs, 1030.5 for control CDs, and
1006.0 for all Australian CDs (t-test P-values: 0.33 for case vs control CDs and <0.001 for
both case and control CDs vs all Australian CDs) (data not shown in tables). These findings
are consistent with the observation that income and education were comparable among cases
and controls (Table 1).
Overall, 22% of mothers smoked preconception, 16.8% of mothers smoked during pregnancy,
29% of fathers smoked in the preconception year and 26% of fathers smoked during the
pregnancy.
Paternal smoking in both periods was moderately correlated with maternal
smoking during pregnancy: Spearman’s = 0.36, P <0.001. Overall, there was little evidence
that maternal or paternal smoking was associated with risk of CBT (Table 2). Although the
ORs for paternal smoking 1-14 CPD in both periods were around 1.3, the estimates lacked
precision due to a relatively small number of smokers, and the ORs for higher levels of
smoking were below the null. The results were similar when parental smoking was mutually
adjusted, when the analysis was restricted to children whose other parent did not smoke (data
6
not shown), and when the reference level was changed to ‘no smoking from 2 years before the
birth year’ for mothers, and ‘no smoking ever before the birth’ for the fathers (data not
shown). The OR for maternal smoking during pregnancy and paternal smoking in the
preconception year was 0.87 (95% CI: 0.50, 1.50). No evidence was seen for associations
with ever smoking, ex-smoking, or increasing pack-years for either parent (results not shown).
When stratified by the child’s age at diagnosis or recruitment, the ORs for maternal smoking,
both preconception and during pregnancy, were high for CBT diagnosed under 24 months of
age, although this was based on small numbers (Table 3). There was no evidence of a similar
age-interaction for paternal smoking (Table 3). There was no evidence of an interaction
between parental smoking and alcohol consumption (data not shown).
For low grade gliomas, the ORs for maternal smoking during pregnancy and paternal smoking
preconception were 1.02 (95% CI 0.62, 1.67) and 1.02 (95% CI 0.66, 1.60) respectively
(results not shown in tables). For PNET/medulloblastoma, the ORs were 0.82 (95% CI 0.39,
1.70) and 0.90 (95% CI 0.47, 1.70) for mother and father respectively. Other subtypes had
insufficient numbers to analyse separately. There were insufficient numbers to investigate
any interaction between smoking and child’s age within CBT subtypes.
Discussion
Overall, neither maternal nor paternal smoking before or during pregnancy was associated
with an increased risk of CBT; these findings are consistent with most previous reports, as
summarised in the introduction. There was an indication that maternal smoking before or
during pregnancy was associated with an increased risk of CBT in infants (less than 24
months old), but this was based on a small number of cases and could be due to chance.
Two previous studies also reported some variation in the association between maternal
smoking during pregnancy and CBT risk by the child’s age. A Swedish cohort study6 reported
an increased risk of CBT among children aged between 2 and 4 years (OR 1.64, 95% CI:
1.15, 2.33), but found little or no evidence of an association at other ages; and a Californian
study18 reported ORs of 0.68 (95% CI: 0 43, 1.1) for CBT among children younger than 6
years, and 1.1 (95% CI: 0.73, 1.6) among older children. No formal assessment of the age by
smoking interactions was reported in these papers. Three additional studies reported no
differences in associations by age.7, 15, 19 Only one previous study investigated possible effect
modification by alcohol use;20 no modification of the overall null association with smoking
was observed. The reasons for the inconsistencies among previous studies of parental
7
smoking are not clear, but may be due to a combination of factors: different windows of
exposure, dose categories and distributions of CBT subtypes; use of proxy respondents,
measurement error, recall bias and lack of investigation of age-specific associations.
An increased risk of CBT among infants associated with maternal smoking during pregnancy
is biologically plausible. Chemicals found in tobacco smoke – including neurocarcinogens –
can cross the placenta21 and cause chromosomal damage in the fetus.22 Animal studies have
shown that the developing brain is much more likely to develop tumors as a result of exposure
to neurocarcinogens in utero than later in life,23 and this may also be the case for humans.
Hence, it is plausible that tumors initiated through tobacco-induced damage to the fetal brain
would manifest themselves relatively early in life. This is consistent with our finding that
maternal smoking appeared to be associated with CBT risk only among very young children.
Almost 78% of eligible cases were invited to participate by the treating clinician and 66% of
invited parents consented, resulting in an overall participation fraction of 51%. Except for age
and sex, where the distributions were similar to participating cases, information about eligible
cases who did not participate was unavailable, so we could not determine whether our cases
were representative of all eligible cases with respect to potential risk factors. Control families
were recruited by national RDD using state-of-the-art methods and, according to the most
recent data available, approximately 90% of Australian households had a landline telephone
connection
during
the
recruitment
period
[http://www.abs.gov.au/AUSSTATS/abs@.nsf/DetailsPage/1367.5Sep%202008]. Therefore,
residences contacted are likely to be representative of the wider population. Telephone-based
methods have been evaluated and shown to perform well in Australia for control subject
recruitment, compared with other methods,24 and RDD is likely to be the best and most costeffective method available.
Participation among eligible control families was 62% and, although no individual
information was available for those who declined, area-based SES scores were higher among
participating controls than among the wider Australian population. However, importantly,
participating cases and controls had very similar SES distributions.
Information about smoking was provided by approximately 81% case and 64% control
mothers, and 66% case and 55% control fathers. Selection bias is possible since control
parents who provided smoking data lived in areas with (on average) higher IRSD scores than
those who did not; thus, they may have a lower prevalence of smoking. However, the
8
prevalence of smoking during pregnancy among our control mothers (16.8%) was similar to
New South Wales Midwives data (population-based surveillance system) for birth years 19952007 (17.2%)25, suggesting that they are representative of the general population with respect
to smoking.
Further, the most likely consequence of selection bias due to the over-
representation of higher SES controls would be inflated ORs for smoking; if this has occurred,
then the true ORs for smoking would be even further below the null, which seems unlikely.
All analyses were adjusted for household income and further adjustment for IRSD or
education did not alter the effect estimates.
Our questionnaires were designed to reduce measurement error by ‘anchoring’ parents’ recall
of smoking to their residence and occupation in each year. Nonetheless, it is plausible that
smoking was recalled less accurately by parents of older children (where the index pregnancy
was further in the past). However, why the ORs among older children tended to be below
unity is not clear, as parental smoking is unlikely to be protective against CBT among
children of any age, and there is little reason to believe that recall of smoking among parents
of older controls would be more complete than among parents of older cases. Given these
results, it is reasonable to infer that the increased ORs observed for infants are not solely due
to bias resulting from over-reporting of smoking among the parents of infant cases.
In summary, this study provides little evidence that parental smoking in the preconception or
pregnancy period is associated with an increased risk of CBT, except possibly among infant
children of smoking mothers. We recommend that future studies investigate the associations
between maternal smoking and risk of CBT by the child’s age of diagnosis.
9
Consortium statement
The Aus-CBT consortium conducted the study and the Telethon Institute for Child Health
Research (TICHR), University of Western Australia, was the coordinating centre. Bruce
Armstrong (Sydney School of Public Health, University of Sydney), Elizabeth Milne,
Nicholas de Klerk, Caroline Bower, Peter Dallas (TICHR), Frank van Bockxmeer (Royal
Perth Hospital, University of WA), Rodney Scott and John Attia (University of Newcastle),
Lin Fritschi (WA Institute for Medical Research), Lesley Ashton, Michelle Haber and Murray
Norris (Children’s Cancer Institute Australia for Medical Research, Lowy Cancer Research
Centre, UNSW), Margaret Miller (Edith Cowan University) and Judith Thompson (WA
Cancer Registry) were the research investigators.
The authors acknowledge the contribution made by our clinical co-investigators who recruited
and cared for study patients at each participating hospital: Nicholas Gottardo (Princess
Margaret Hospital, TICHR); John Heath and Elizabeth Smibert (Royal Children’s Hospital,
Melbourne); Peter Downie (Monash Medical Centre, Melbourne); Tim Hassell and Ross
Pinkerton (Royal Children’s Hospital Brisbane); Maria Kirby (Women’s and Children’s
Hospital, Adelaide); Stewart Kellie and Luciano dalla Pozza (Children’s Hospital at
Westmead); Frank Alvaro (John Hunter Hospital, Newcastle); Richard Cohn (Sydney
Children’s Hospital) and John Daubenton (Royal Hobart Hospital).
The authors also acknowledge the Clinical Research Associates at each hospital, and the study
coordinators: Jackie Mansour, Somer Dawson, Tamika Heiden, and Helen Bailey.
Funding: The National Health and Medical Research Council (NHMRC) funded Aus-ALL
(Grant number: 254539) and Aus-CBT (Grant number: 404089).
Elizabeth Milne was
supported by an NHMRC Fellowship. Support for Rodney Scott was in part from NBN
Children's Cancer Research Fund.
10
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13
Table 1: Distribution of demographic and birth characteristics in the Australian Study
of Childhood Brain Tumors, 2005-2010.
Child gender
Female
Male
0-1
2-4
5-9
10-14
NSW/ACT
Victoria/Tasmania
SA/NT
Western Australia
Queensland
1990-1997
1998-2003
2004-2010
2005-2006
122
180
30
85
89
98
102
85
19
42
54
84
125
93
107
40.4
59.6
9.9
28.1
29.5
32.5
33.8
28.1
6.3
13.9
17.9
27.1
41.4
30.8
35.4
445
496
110
303
293
235
283
251
77
112
218
223
469
249
415
47.3
52.7
11.7
32.2
31.1
25.0
30.1
26.7
8.2
11.9
23.2
23.7
49.8
26.5
44.1
2007-2008
2009-2010
≤24
25-34
35+
<24
25-34
35+
Didn’t complete
secondary school
Complete
secondary school
and/or trade
certificate
University/College
Up to $40, 000
$40, 001-$70,000
$70,001-$100,000
>$100, 000
1
2
3+
European
At least 50%
99
96
45
187
70
15
151
100
42
32.8
31.8
14.9
61.9
23.2
5.6
56.8
37.6
13.9
268
258
87
593
261
26
434
335
91
28.5
27.4
9.2
63.0
27.7
3.3
54.6
42.1
9.7
99
32.8
301
32.0
161
49
78
80
93
138
98
66
185
73
53.3
16.3
26.0
26.7
31.0
45.7
32.5
21.9
61.3
24.2
549
127
262
249
299
399
326
216
679
170
58.3
13.6
28.0
26.6
31.9
42.4
34.6
23.0
72.2
18.1
Child state residenceb
Birth year
Year of diagnosis/
Recruitment
Maternal age group
Paternal age group
Best parental education
Household income
Birth order
Ethnic groupc
14
Control n
1363
Control %a
Category
Child age group
Case n
335
Case %a
Variable
Provided demographic
data
Mother returned exposure
questionnaire
Father returned exposure
questionnaire
302
941
247
801
European
At least 50% non12
4.0
30
3.2
European
Indeterminate
32
10.6
62
6.6
Tumor diagnosis
Low grade
144
47.7
gliomas
High grade
26
8.6
gliomas
Embryonal
71
23.5
tumorsd
Germ cell tumors
20
6.6
Ependymomas
22
7.3
e
Others
19
6.3
a
Percentages are of participants whose mother returned the exposure questionnaire.
b
ACT: Australian Capital Territory; NSW, New South Wales; NT, Northern Territory; SA,
South Australia.
c
European, at least 3 European grandparents; 50% European, 2 European grandparents; at
least 50% non-European, 2 non-European grandparents and ethnicity of 2 other grandparents
non-European or unknown; indeterminate, no 2 grandparents of same ethnicity (i.e European
or non-European) and 2+ grandparents of unknown ethnicity.
d
Includes 46 medulloblastomas, 22 primitive neuroectodermal tumors, 3 atypical teratoid
rhabdoid tumors.
e
Includes 6 meningiomas, 9 choroid plexus tumors, 4 unclassified.
15
Table 2: Association between parental smoking before and during the pregnancy and
risk of childhood brain tumors
Case n
Maternal smoking preconceptiona
None
228
1-14 CPD
41
15+ CPD
31
Any
72
P-value for dose trend
%
Control n
%
OR
95% CI
76.0
13.7
10.3
24.0
731
101
105
206
78.0
10.8
11.2
22.0
1.00
1.16
0.82
0.99
Referent
0.76, 1.78
0.52, 1.31
0.70, 1.40
0.61
780
85
72
157
83.2
9.1
7.7
16.8
1.00
0.91
0.88
0.89
Referent
0.56, 1.47
0.52, 1.49
0.61, 1.31
0.57
Maternal smoking during pregnancya
None
249
1-14 CPD
28
15+ CPD
23
Any
51
P-value for dose trend
83.0
9.3
7.7
17.0
Paternal smoking preconceptionb
None
168
69.4
568
71.9
1.00
Referent
1-14 CPD
32
13.2
71
9.0
1.31
0.82, 2.11
15+ CPD
42
17.4
151
19.1
0.83
0.55, 1.24
Any
74
30.6
222
28.1
0.99
0.71, 1.38
P-value for dose trend
0.54
b
Paternal smoking during pregnancy
None
171
70.7
588
74.4
1.00
Referent
1-14 CPD
29
12.0
65
8.2
1.30
0.79, 2.13
15+ CPD
42
17.3
137
17.4
0.92
0.61, 1.38
Any
71
29.3
202
25.6
1.04
0.74, 1.46
P-value for dose trend
0.85
a
Adjusted for matching variables, child’s ethnicity, year of birth group, mother’s age group,
alcohol consumption during pregnancy, household income.
b
Adjusted for matching variables, child’s ethnicity, year of birth group, father’s age group,
household income.
16
Table 3: Parental smoking stratified by child’s age at diagnosis or recruitment
Age
Smoking
n Case/Controls
OR
95% CI
P-value of
Interaction
a
Maternal smoking preconception
0-1
None
20/93
1.00
Referent
0.09
Any
10/17
5.06
1.35, 19.00
2-4
None
65/241
1.00
Referent
Any
20/60
1.34
0.69, 2.60
5-9
None
71/226
1.00
Referent
Any
18/67
0.78
0.39, 1.54
10-14
None
72/171
1.00
Referent
Any
24/62
0.61
0.32, 1.16
Maternal smoking during pregnancy a
0-1
None
23/98
1.00
Referent
0.10
Any
7/12
4.61
1.08, 19.63
2-4
None
71/251
1.00
Referent
Any
14/50
1.00
0.48, 2.07
5-9
None
79/244
1.00
Referent
Any
10/49
0.60
0.26, 1.35
10-14
None
76/187
1.00
Referent
Any
20/46
0.73
0.36, 1.47
Paternal smoking preconception b
0-1
None
20/80
1.00
Referent
0.25
Any
6/24
1.11
0.29, 4.20
2-4
None
47/190
1.00
Referent
Any
28/68
1.45
0.79, 2.68
5-9
None
54/176
1.00
Referent
Any
19/69
0.74
0.38, 1.44
10-14
None
47/122
1.00
Referent
Any
21/61
0.75
0.39, 1.44
Paternal smoking during pregnancy b
0-1
None
20/82
1.00
Referent
0.26
Any
6/22
1.48
0.39, 5.65
2-4
None
49/198
1.00
Referent
Any
26/60
1.61
0.86, 3.01
5-9
None
55/182
1.00
Referent
Any
18/63
0.75
0.38, 1.49
10-14
None
47/126
1.00
Referent
Any
21/57
0.82
0.43, 1.60
a
Adjusted for matching variables, child’s ethnicity, year of birth group, mother’s age group,
alcohol consumption during pregnancy, household income.
b
Adjusted for matching variables, child’s ethnicity, year of birth group, father’s age group,
household income.
17