Upload
jareth-lau
View
217
Download
0
Embed Size (px)
Citation preview
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 1/6
http://jdr.sagepub.com/ Journal of Dental Research
http://jdr.sagepub.com/content/89/3/307The online version of this article can be found at:
DOI: 10.1177/0022034509356779
2010 89: 307 originally published online 21 January 2010J DENT RES
W.M. Thomson, S.M. Williams, J.M. Broadbent, R. Poulton and D. LockerLong-term Dental Visiting Patterns and Adult Oral Health
Published by:
http://www.sagepublications.com
On behalf of:
International and American Associations for Dental Research
can be found at:Journal of Dental Research Additional services and information for
http://jdr.sagepub.com/cgi/alertsEmail Alerts:
http://jdr.sagepub.com/subscriptionsSubscriptions:
http://www.sagepub.com/journalsReprints.navReprints:
http://www.sagepub.com/journalsPermissions.navPermissions:
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 2/6
307
DOI: 10.1177/0022034509356779
Received December 18, 2008; Last revision August 3, 2009;
Accepted September 22, 2009
W.M. Thomson1*, S.M. Williams2, J.M. Broadbent3, R. Poulton2, andD. Locker4
1Department of Oral Sciences, Sir John Walsh Research
Institute, Faculty of Dentistry, University of Otago, Dunedin,
New Zealand; 2Department of Preventive and Social Medicine,
Dunedin School of Medicine, University of Otago, Dunedin,
New Zealand; 3Dunedin Multidisciplinary Health and
Development Research Unit, Department of Preventive
and Social Medicine, Dunedin School of Medicine, University
of Otago, Dunedin, New Zealand; and 4Community
Dental Health Services Research Unit, Faculty of Dentistry,
University of Toronto, ON, Canada; *corresponding author,
J Dent Res 89(3):307-311, 2010
AbAcTo date, the evidence supporting the benefits of
dental visiting comes from cross-sectional studies.
We investigated whether long-term routine dental
visiting was associated with lower experience of
dental caries and missing teeth, and better self-
rated oral health, by age 32. A prospective cohort
study in New Zealand examined 932 participants’
use of dentistry at ages 15, 18, 26, and 32. At each
age, routine attenders (RAs) were identified as
those who (a) usually visited for a check-up, and
(b) had made a dental visit during the previous 12
months. Routine attending prevalence fell from
82% at age 15 to 28% by 32. At any given age,routine attenders had better-than-average oral
health, fewer had teeth missing due to caries, and
they had lower mean DS and DMFS scores. By
age 32, routine attenders had better self-reported
oral health and less tooth loss and caries. The lon-
ger routine attendance was maintained, the stron-
ger the effect. Routine dental attendance is
associated with better oral health.
KEY WOD: oral health, utilization, dental
visiting.
INODUcION
he adult users of dental services can be categorized into routine attenders and
problem-oriented attenders (Gilbert et al., 2000). Promoting regular dental
visits is one of the cornerstones of preventive dentistry (Axelsson et al., 1991;
Murray, 1996; Richards and Ameen, 2002), but, typically, only about half of
the adult population in most Western countries are routine attenders (Roberts-
Thomson et al ., 1995; Jamieson and Thomson, 2002), with rates being lower
among men and in particular social, ethnic, or age groups (Roberts-Thomson
et al., 1995; Dixon et al., 1999; Green et al ., 2003), and higher in Scandinavia
(Hjern et al., 2001). There is epidemiological evidence showing that problem-
oriented attenders have poorer oral health than routine attenders, even after
adjustment for putative confounders such as social class, age, gender, and
ethnicity, but almost all of that comes from cross-sectional studies. One excep-
tion, a cohort study of young New Zealand adults, found that problem-oriented
attenders were three times more likely to experience caries-associated tooth
loss over an eight-year period (Thomson et al., 2000). Such differences are not
confined to clinical measures: A recent UK study of a representative sample
of adults found that problem-oriented attenders had poorer oral-health-related
quality of life (McGrath and Bedi, 2001). A US study of older adults reported
that the prevalence of “oral disadvantage” (defined according to a range of self-
reported measures) was greater among problem-oriented attenders, even after
adjustment for clinical measures (Gilbert et al., 1997).
It is currently unclear whether the difference between problem-oriented
and routine attenders is due to the routine visiting itself—that is, that dental
attendance and the associated preventive (and interceptive) care and advice
are efficacious—or whether it is because of a “healthy user” effect (Posthuma
et al ., 1994): Routine attenders have better oral health and health behaviors
anyway. A recent systematic review was inconclusive (Davenport et al.,
2003), owing to a shortage of appropriate, high-quality studies. It would be an
unusual society which permitted random allocation of its citizens to particular
dental attendance patterns for the purposes of a randomized control trial.
Thus, the most useful higher-level source of information on the issue is likely
to be a prospective cohort study where a (preferably representative) sample is
followed for long enough to determine whether routine dental attendance is
contributing to routine attenders’ better oral health over and above their better
oral health behavior.
Long-term Dental VisitingPatterns and Adult Oral Health
EEAcH EPOclinial
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 3/6
308 Thomson et al. J Dent Res 89(3) 2010
The aim of this study was to determine whether long-term rou-
tine dental attenders had (a) better self-rated oral health and (b)
lower experience of dental caries and missing teeth by age 32.
MAEIAL & MEHOD
The Dunedin Multidisciplinary Health and Development Study
is a longitudinal study of a birth cohort born in Dunedin (NewZealand) between 1 April 1972 and 31 March 1973 (Silva and
Stanton, 1996). The sample that formed the basis for the longi-
tudinal study was 1037 children assessed within a month of their
third birthdays and is considered to be broadly representative of
its age group in the South Island population. Periodic collections
of health and developmental data have since been undertaken,
and this study uses data collected from assessments conducted
at ages 15, 18, 26, and 32. Over 90% of the cohort self-identified
as European. Ethical approval for the study was obtained from
the Otago Ethics Committee, and informed consent was obtained
from each participant (and also from parents at the assessments
conducted during adolescence).
Use of Dental ervies
Information on use of dental services was collected at ages 15, 18,
26, and 32, and was determined differently as participants aged.
The assumption was made that all were routine attenders before age
15, since the New Zealand School Dental Service provided routine
care to almost all children at that time (and the small number who
had opted out are believed to have routinely sought private dental
care) (Thomson, 2001). At ages 15 and 18, participants were asked
whether they were enrolled with the General Dental Benefit scheme
(whereby NZ adolescents were entitled to receive free routine den-
tal care) and about the time since their last dental visit (and the
reason for it). At ages 26 and 32, use of dental services was deter-
mined by asking participants whether they usually visited the den-tist for a check-up or only when a dental problem arose, together
with the number of months since the last visit. For each of ages 15,
18, 26, and 32, routine attenders were identified as those who (a)
usually visited for a check-up, and (b) had made a dental visit dur-
ing the previous 12 months.
Dependent Variales
At each age, dental examinations for caries (collected as sur-
face-level data) and missing teeth were conducted by calibrated
dental examiners, who obtained an estimate of accumulated
tooth loss due to caries by observing the presence or absence of
each tooth, and ascertaining the reason for its absence. In thisstudy, third molars were not included in the computation of
tooth loss; only those teeth which had been lost because of car-
ies were included. Self-rated oral health was measured by ask-
ing participants to rate their oral health in comparison with that
of other persons their age (with response options: ‘among the
nicest’, ‘better than average’, ‘worse than average’, or ‘among
the worst’). The dependent variables used in the current study
were mean DMFS and mean DS, the prevalence of 1+ teeth
missing due to caries, and self-reported oral health (as a binary
variable) by age 32.
covariates
We measured socio-economic status (SES) by using data col-
lected on parental socio-economic status, using standard New
Zealand occupationally based indices (Irving and Elley, 1977;
Elley and Irving, 1985), which involve a 6-category classifica-
tion (where, for example, a doctor scores ‘1’ and a laborer scores
‘6’). Childhood SES was calculated as the average of the highest
SES level of either parent, assessed repeatedly from birth to 15
years. Participants were classified as having low (groups 5 and
6), medium (groups 3 and 4), or high (groups 1 and 2) childhood
SES. SES in adulthood was classified the same way, but using
the participant’s occupation at age 32.
Dental plaque accumulation was measured at ages 15, 18, 26,
and 32 according to the Simplified Oral Hygiene Index (Greene
and Vermillion, 1964). Because we had no direct measure of
self-care at any age (other than self-reported toothbrushing fre-
quency), plaque scores were used to represent self-care (as one
directly observable measure of the efficacy of that self-care) to
determine whether a “healthy user” effect existed.
Data Analysis
Following the computation of descriptive statistics, we fitted mod-
els using generalized estimating equations (GEE) methods in Stata,
according to a recently described approach (Pepe et al., 1999). The
aim was to estimate the strength of the association between regular
dental visiting and the outcome variable of interest (the “univariate
association”) at each assessment. A non-standard GEE with an
independent correlation matrix provided an appropriate covariance
matrix for these comparisons to be made. Further analyses adjusted
for sex and SES (and for plaque score in subsequent modeling) at
each assessment. Because pairwise comparisons of the 4 assess-
ments involved 6 statistical tests, the Bonferroni inequality test was
used to adjust the type 1 error rate, so comparisons in the modelswere regarded as statistically significant for P < 0.008.
EUL
Participation rates in the Dunedin Study are high, with 972 partici-
pants (96%) taking part in the age-32 assessment; 932 (96%) of
those were dentally examined. The 40 who were not dentally exam-
ined did not differ from the latter in terms of gender, but there was
a slight difference by childhood SES group (high 98.1%; medium
96.3%; low 92.9%; P = 0.04). The current analyses involved those
932 individuals (51.1% of whom were male). Complete service-use
data were available for 739 individuals at age 15, 823 at age 18, 904
at age 26, and 916 at age 32.The prevalence of routine attending fell from just over four-
fifths at age 15 to about one in four by age 32 (Table 1). Just over
one in ten were routine attenders at each of ages 15, 18, 26, and 32
(“long-term routine attenders”). An age-associated divergence was
apparent between men and women, and more of the latter were
long-term routine attenders. All three SES groups showed a decline
in routine attendance with age: An apparent lack of a SES differ-
ence at age 15 had become quite a gradient by age 18 (whereby it
was lowest among low-SES individuals and highest among those
of high SES), and it was marked by ages 26 and 32.
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 4/6
J Dent Res 89(3) 2010 Visiting Patterns and Oral Health 309
ale 1. Dental Visiting Status at Ages 15, 18, 26, and 32, by Sex and Socio-economic Status (brackets contain percentages)
Sex Socio-economic statusa
Number (%)b Female Male High Medium Low
Age 15Routine attenders 604 (81.7) 304 (83.3) 300 (80.2) 105 (84.0) 391 (81.0) 107 (82.3)Non-routine attenders 135 (18.3) 61 (16.7) 74 (19.8) 20 (16.0) 92 (19.0) 23 (17.7)
Age 18Routine attenders 549 (66.7) 271 (66.9) 278 (66.5) 99 (74.4) 367 (68.6) 80 (53.0)c
Non-routine attenders 363 (33.3) 134 (33.1) 140 (33.5) 34 (25.6) 168 (31.4) 71 (47.0)Age 26
Routine attenders 282 (31.2) 151 (33.9) 131 (28.5) 58 (38.7) 179 (31.2) 44 (25.0)c
Non-routine attenders 622 (68.8) 294 (66.1) 328 (71.5) 92 (61.3) 394 (68.8) 132 (75.0)Age 32
Routine attenders 254 (27.7) 139 (30.9) 115 (24.7)c 55 (36.4) 160 (27.5) 38 (21.3)c
Non-routine attenders 662 (72.3) 311 (69.1) 351 (75.3) 96 (63.6) 422 (72.5) 140 (78.7)Ages 15 to 32
Routine attenders 102 (10.9) 65 (14.3) 37 (7.8)b 18 (11.8) 69 (11.7) 15 (8.2)Non-routine attenders 830 (89.1) 391 (85.7) 439 (92.2) 134 (88.2) 522 (88.3) 169 (91.8)
All combined 932 (100.0) 456 (48.9) 476 (51.1) 152 (16.4) 591 (63.8) 184 (19.8)
a Five cases unable to be classified.b Numbers with complete service-use data: 739 at age 15; 823 at age 18; 904 at age 26; and 916 at age 32.c P < 0.05.
ale 2. Oral Health or Disease at Age 32 by Dental Visiting Status at Ages 15, 18, 26, and 32
Self-rated Oral Health‘better than average’ (%)a
1+ Teeth Missing Dueto Dental Caries (%)
Mean Number ofDecayed Surfaces (SD) Mean DMFS (SD)
Age 15b Routine attenders 336 (55.9) 123 (20.4)c 1.9 (3.7)c 15.9 (14.1)c
Non-routine attenders 56 (41.5) 35 (25.9) 2.8 (5.1) 18.8 (18.6)Age 18b
Routine attenders 311 (57.0)c 99 (18.0)c 1.7 (3.6)c 15.1 (14.0)c
Non-routine attenders 116 (42.5) 86 (31.4) 3.2 (5.7) 20.2 (18.3)Age 26b
Routine attenders 190 (67.4)c 30 (10.6)c 1.3 (3.8)c 14.3 (13.8)c
Non-routine attenders 281 (45.4) 178 (28.6) 2.6 (4.7) 17.5 (15.8)Age 32b
Routine attenders 187 (73.9)c 35 (13.8)c 1.2 (2.6)c 14.7 (12.8)c
Non-routine attenders 288 (43.6) 174 (26.3) 2.7 (5.1) 17.3 (12.8)Ages 15 to 32
Always a routine attender 82 (80.4)c 12 (11.8)c 1.1 (2.8)c 15.1 (14.7)c
Others 350 (51.5) 146 (21.4) 2.0 (4.0) 16.0 (14.2)Never a routine attender 47 (32.0) 61 (41.5) 4.9 (7.5) 21.3 (19.8)
All combined 479 (51.6) 219 (23.5) 2.4 (4.8) 16.8 (15.4)
a Four missing cases.b Numbers with complete service-use data: 739 at age 15; 823 at age 18; 904 at age 26; and 916 at age 32.c P < 0.05.
Those who were routine attenders at a given age had a higher
proportion reporting better-than-average oral health and a lower
proportion with caries-associated tooth loss (Table 2). For example,
at age 32, 67.4% of those who were routine attenders at age 26—
but only 45.4% of those who were not—rated their oral health as
better than average. Similarly, routine attenders had fewer untreated
decayed surfaces (on average) and lower mean DMFS scores by
age 32. When the patterns from ages 15 to 32 were examined, long-
term routine attenders had more favorable scores on all indicators,
particularly in comparison with those who were never routine
attenders. For example, the latter’s mean number of untreated
decayed surfaces by age 32 was more than 4 times that of the long-
term routine attenders; the overall mean DMFS difference was just
over 5 surfaces, and there were also marked gradients in tooth-loss
experience and self-rated oral health.
Some 147 (15.8%) were routine attenders at none of the 4
ages, 220 (23.6%) at 1 age, 308 (33.0%) at 2 ages, 155 (16.6%)
at 3 ages, and 102 (10.9%) at all 4 ages. This categorization by
the number of ages of routine attendance was strongly associ-
ated with self-reported oral health and caries-associated missing
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 5/6
310 Thomson et al. J Dent Res 89(3) 2010
0
10
20
30
40
50
60
70
80
90
100
1+ teeth missing due to caries Self-rated oral health ‘better than average’
%
0 ages 1 age 2 ages 3 ages 4 ages
Figure a. Gradients in age-32 prevalence of caries-associated toothloss and better-than-average self-rated oral health by the number ofassessment ages at which participants were routine attenders [147(15.8%) were routine attenders at no age, 220 (23.6%) at 1 age, 308
(33.0%) at 2 ages, 155 (16.6%) at 3 ages, and 102 (10.9%) wereroutine attenders at all 4 ages; error bars depict standard errors].
0
5
10
15
20
25
Mean DMFS at 32 Mean DS at 32
M e a n
0 ages 1 age 2 ages 3 ages 4 ages
Figure . Gradients in age-32 mean DMFS and DS scores, by thenumber of assessment ages at which participants were routine attenders[147 (15.8%) were routine attenders at no age, 220 (23.6%) at 1 age,308 (33.0%) at 2 ages, 155 (16.6%) at 3 ages, and 102 (10.9%) wereroutine attenders at all 4 ages; error bars depict standard errors].
teeth (Fig., a) and with mean DMFS and DS scores by age 32
(Fig., b): There were generally less-favorable scores among
those who had been routine attenders at fewer ages.
The models comparing the associations between the 4 oral
health outcomes and routine attendance at the 4 ages (Table 3) first
controlled for sex and SES, after which plaque scores for each of
ages 15, 18, 26, and 32 were also entered (as proxies for self-care,
in an attempt to adjust for a “healthy user” effect). In interpreting
the model outcomes, it is important to bear in mind that the ORs
and IRRs for each age represent the univariate estimate, adjusted
for the covariates. Thus, someone who was a routine attender at age
15 had 1.70 times the odds of an age-15 non-routine attender of
reporting better-than-average oral health by age 32. Moreover, with
the exception of age 18, the closer the age was to 32, the greater the
OR, with an age-32 routine attender having 3.36 times the odds.
Similarly, the odds of having caries-associated tooth loss by age 32
were lower for routine attenders regardless of age, but they were
lowest for age-26 routine attenders. The models for age-32 DS and
DMFS confirmed that routine attendance predicted lower scores,
but there were no clear patterns with respect to age, other than age-
32 routine attenders having the lowest IRR for mean DS.
DIcUION
This study aimed to determine whether long-term routine dental
attenders had better self-rated oral health and lower experience of
dental caries and missing teeth by age 32 than those with less-
favorable visiting patterns. We found that routine attenders have
better self-reported oral health and less tooth loss and dental caries.
We also observed that the differential was greater with longer expo-
sure to routine attendance, with long-term routine attenders having
the best oral health by age 32. Analysis of the data also suggested
that, for decayed surfaces and self-rated oral health, more proximal
exposure to routine attendance is beneficial.
It is appropriate to consider first the weaknesses and strengths of
the study. For example, the dental attendance data were self-
reported, and we were unable to verify each participant’s dental
utilization independently. Moreover, the collected information per-
tained to the individual’s usual dental visiting pattern at that age,
and it is possible that some may have changed their pattern (e.g.,
from non-routine to routine and back to non-routine between
assessments); thus, there is likely to be a degree of inaccuracy in
exposure measurement. Underlying the entire approach is the
assumption (unable to be tested here) that the benefits of routine
attendance are similar regardless of who the dentist is. The study’s
strengths lie in its prospective design, high retention rate after three
decades, and its mix of clinical and self-report outcome measures.
Analyses such as this are rare because of the scarcity of prospective
oral health studies of birth cohorts (particularly through adulthood).
Turning to the research question, what are the effects of long-
term routine dental attendance? Does repeated exposure to dental
check-ups and advice (and whatever one-on-one prevention is
available) over many years actually have an effect, or are there ten-
able alternative hypotheses which might explain the findings? The
strength of the observed association between long-term routine use
and better oral health is indisputable, particularly with missing
teeth, self-rated oral health, and untreated caries. The findings with
respect to the overall caries experience represented by age-32
DMFS are not quite as straightforward, with little difference among
those who were routine attenders at 2, 3, or 4 ages, a finding which
is most likely attributable to routine attenders’ higher likelihood of
receiving restorative treatment (Baelum, 2008).
However, the crux of the issue is the extent to which the
“healthy user” effect was responsible for at least some of the
observed differences between routine attenders and the remain-
der: They probably differ in ways that are hard to measure but
likely to result in better oral health. Sex and SES are two such
factors, and we controlled for those accordingly. It might also be
expected that (all other factors being equal) routine attenders are
likely to have cleaner teeth than problem-oriented attenders, and
so we controlled for that using plaque scores measured at each
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research
8/6/2019 JDR_ExampleforReferencing
http://slidepdf.com/reader/full/jdrexampleforreferencing 6/6
J Dent Res 89(3) 2010 Visiting Patterns and Oral Health 311
ale 3. Estimates (and 95% confidence intervals) for the Association between Routine Dental Attendance at Ages 15, 18, 26, and 32 (adjustedfor sex and socio-economic status) and Oral Health Outcomes by Age 32
Routine Attendance at Age:
15 18 26 32
Models without plaque scoresSelf-rated oral health ‘better than average’a 1.78c (1.22, 2.60) 1.73d (1.29, 2.32) 2.49e (1.85, 3.34) 3.51c d e (2.54, 4.84)1+ teeth missing due to dental cariesa 0.73c (0.46, 1.16) 0.54d (0.38, 0.76) 0.30c d e (0.20, 0.46) 0.50e (0.33, 0.75)Mean number of decayed surfacesb 0.65 (0.44, 0.95) 0.59 (0.44, 0.78) 0.53 (0.37, 0.75) 0.48 (0.35, 0.65)Mean DMFSb 0.84 (0.71, 1.01) 0.78 (0.69, 0.89) 0.82 (0.71, 0.93) 0.89 (0.79, 1.01)
Models with plaque scoresSelf-rated oral health ‘better than average’a 1.70c (1.16, 2.50) 1.52d (1.12, 2.05) 2.24e (1.65, 3.03) 3.36c d e (2.42, 4.66)1+ teeth missing due to dental cariesa 0.75c (0.47, 1.20) 0.66d (0.46, 0.95) 0.35c d e (0.23, 0.54) 0.54e (0.36, 0.82)Mean number of decayed surfacesb 0.64 (0.42, 0.96) 0.67 (0.49, 0.90) 0.60 (0.43, 0.84) 0.54 (0.40, 0.73)Mean DMFSb 0.86 (0.71, 1.02) 0.83 (0.73, 0.95) 0.86 (0.75, 0.98) 0.93 (0.82, 1.05)
a Estimates are odds ratios (OR).b Estimates are incidence rate ratios (RR).c,d,e Estimates with different symbols are significantly different from each other (by post hoc criteria).
of the 4 assessment ages. After adjustment for those effects, the
beneficial effect of routine dental attendance persisted; that thedifference made by adjustment for plaque scores (as directly
observable measures of dental self-care at each of the 4 ages)
was not a great one suggests perhaps that dental visiting has a
relatively strong effect. It may, of course, be that the routine
attenders’ regular exposure to the dental care environment and
associated oral health messages influenced their self-care behav-
ior (and consequently their plaque scores); however, investigat-
ing this issue is beyond the scope of the current study.
In conclusion, this prospective study supports the notion that
routine dental attendance is associated with better oral health
outcomes. It is therefore appropriate for current oral health mes-
sages to strongly promote regular dental visiting.
AcKNOWLEDGMEN
This work was supported by: Grant R01 DE-015260 from the
National Institute of Dental and Craniofacial Research, National
Institutes of Health, Bethesda, MD 20892, USA; and by a program
grant from the Health Research Council of New Zealand.
EFEENcEAxelsson P, Lindhe J, Nyström B (1991). On the prevention of caries and
periodontal disease: results of a 15-year longitudinal study in adults. J Clin
Periodontol 18:182-189.
Baelum V (2008). Caries management: technical solutions to biological
problems or evidence-based care? J Oral Rehabil 35:135-151.
Davenport CF, Elley KM, Fry-Smith A, Taylor-Weetman CL, Taylor RS
(2003). The effectiveness of routine dental checks: a systematic review
of the evidence base. Br Dent J 195:87-98.
Dixon GS, Thomson WM, Kruger E (1999). The West Coast Study I: self-
reported dental health and use of dental services. NZ Dent J 95:38-43.
Elley WB, Irving JC (1985). The Elley-Irving socio-economic index 1981
Census revision. NZ J Educ Stud 20:115-128.
Gilbert GH, Duncan RP, Heft MW, Dolan TA, Vogel WB (1997). Oral dis-
advantage among dentate adults. Community Dent Oral Epidemiol
25:301-313.Gilbert GH, Foerster U, Dolan TA, Duncan RP, Ringelberg ML (2000).
Twenty-four month coronal caries incidence: the role of dental care and
race. Caries Res 34:367-379.
Green BL, Person S, Crowther M, Frison S, Shipp M, Lee P, et al . (2003).
Demographic and geographic variations of oral health among African
Americans based on NHANES III. Community Dent Health 20:117-122.
Greene JC, Vermillion JR (1964). The simplified oral hygiene index. J Am
Dent Assoc 68:7-13.
Hjern A, Grindefjord M, Sundberg H, Rośen M (2001). Social inequality in
oral health and use of dental care in Sweden. Community Dent Oral
Epidemiol 29:167-174.
Irving JC, Elley WB (1977). A socio-economic index for the female labour
force in New Zealand. NZ J Educ Stud 12:154-163.
Jamieson LM, Thomson WM (2002). Dental health, dental neglect, and use
of services in an adult Dunedin population sample. NZ Dent J 98:4-8.
McGrath C, Bedi R (2001). Can dental attendance improve quality of life?
Br Dent J 190:262-265.
Murray JJ (1996). Attendance patterns and oral health. Br Dent J 181:339-342.
Pepe MS, Whitaker RC, Seidel K (1999). Estimating and comparing uni-
variate associations with application to the prediction of adult obesity.
Stat Med 18:163-173.
Posthuma WF, Westendorp RG, Vandenbroucke JP (1994). Cardioprotective
effect of hormone replacement therapy in postmenopausal women: is
the evidence biased? BMJ 308:1268-1269.
Richards W, Ameen J (2002). The impact of attendance patterns on oral
health in a general dental practice. Br Dent J 193:697-702.
Roberts-Thomson K, Brennan DS, Spencer AJ (1995). Social inequality in
the use and comprehensiveness of dental services. Aust J Public Health
19:80-85.
Silva PA, Stanton WR (1996). From child to adult: the Dunedin
Multidisciplinary Health and Development Study. Auckland: Oxford
University Press.
Thomson WM (2001). Use of dental services by 26-year-old New
Zealanders. NZ Dent J 97:44-48.
Thomson WM, Poulton R, Kruger E, Boyd D (2000). Socio-economic and
behavioural risk factors for tooth loss from age 18 to 26 among partici-
pants in the Dunedin Multidisciplinary Health and Development Study.
Caries Res 34:361-366.
at University of Otago on June 22, 2011 For personal use only. No other uses without permission. jdr.sagepub.comDownloaded from
© 2010 International & American Associations for Dental Research