International Journal of Pediatrics
Volume 2016 (2016), Article ID 6123065, 10 pages
http://dx.doi.org/10.1155/2016/6123065

Research Article

Biodemographic Analysis of Factors Related to Perinatal Mortality in Portugal (1988–2011)

Vicente Fuster

Complutense University of Madrid, Department of Zoology and Physical Anthropology, Faculty of Biology, Madrid, Spain

Received 6 July 2016; Revised 27 August 2016; Accepted 18 September 2016

Academic Editor: Naveed Hussain

Copyright © 2016 Vicente Fuster. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

Abstract.

Background. The purpose of this paper is to determine the relative mortality risks at delivery and during the first week of life with regard to maternal and foetal characteristics. Methods. Yearly individual digital records on live births and early neonatal mortality were used to infer the possible factors involved in perinatal deaths. Results. The results show that the number of births per year declined with time throughout the period studied. At the same time, rates decreased in 66.4% for stillbirths and in 70.2% for early neonatal mortality. Logistic regressions modelled the interaction of the two mortality indicators and covariables such as birth weight and the duration of gestation. Conclusions. This research provides a first biodemographic approach to the knowledge of factors influencing perinatal mortality in Portugal based on a set of foetal and maternal variables. Although the magnitude of the different perinatal mortality rates may be affected by the criteria used for selecting cases (multiple-singletons; minimum birth weight or minimum duration of gestation), one of the conclusions of the present analysis is that the relationship among the maternal and foetal variables that determine the relative risk remains unaltered. Certain resemblance with the factors determining negative birth outcomes in Spain is appreciated.

1. Introduction

Perinatal mortality is estimated by the addition of stillbirths plus the early neonatal mortality, which represents deaths occurring during the first seven days after delivery. However, the criteria for determining both perinatal components are diverse. Due to the lack of uniformity in the birth outcome definitions, the comparison of rates among countries may be problematic [1]. This is true for stillbirths for which alternative definitions have been provided [2] depending on the application of thresholds for the gestational age or the birth weight, commonly 28 weeks or 500 g. The value of 28 weeks strictly represents late fetal deaths while early stillbirths are restricted to 20–27 weeks of gestation [3]. For a correct estimation of the stillbirth rates (stillbirths divided by stillbirths plus live births) the limits applied for considering the existence of a stillbirth should also be taken into account when determining the denominator, for example, including only stillbirths and live births of at least 28 weeks of gestation [4]. The advantage of calculating perinatal mortality rates by combining stillbirth with early neonatal mortality is the reduction of the bias due to the definition followed [5].

Although the World Health Organization (WHO) has tried to normalize the definition of perinatal mortality, discrepancies persist among countries [6]. According to some authors it is thought that gestational age is more decisive than birth weight concerning perinatal mortality, while taken into account a minimum birth weight could be affected by the average birth weight. For a set of European countries foetal mortality rates based on gestational ages of 28 weeks produced higher rates than those obtained considering birth weights of at least 1000 g. For the neonatal mortality rate the influence of the criteria applied is less relevant [1]. In a different study, cases with birth weight < 500 or < 1000 g and gestational ages < 24 or < 28 weeks were analyzed [7], while in another [8], it was concluded that because it is a predictor of maturity and viability, a minimum gestational age threshold such as 28 weeks would be more appropriate than a birth weight criterion.

For national statistics the inscription of stillbirths and live births could vary and low thresholds such as gestation ages of at least 22 weeks or birth weights ≥500 g are acceptable. However, for intercountry comparisons standardization should be preferable in agreement with WHO recommendations: ≥28 weeks or ≥1000 g [6].

With regard to the factors possibly determining perinatal mortality, weight and prematurity are recognised as the most important conditions causing stillbirths [9]. The likelihood of stillbirth starts to accelerate as mothers reach the age of 35 and increases with age, raising more quickly after age of 40 [10].

Socioeconomic and cultural factors are also reported to have an influence on birth outcomes. Stillbirth rates tend to increase in association with drug abuse [11], which is more prevalent among less educated women [12].

Unfavourable working conditions result in low socioeconomic status which in turn leads to low levels of schooling. Both factors induce an increased risk of stillbirth [13]. Workers with lower social status in Sweden had a higher risk of stillbirth compared to senior white-collar workers [14]. This issue has also been studied in terms of maternal origin and ethnic group [15, 16]. Working conditions among immigrants can be expected to be less favourable than those of the native population.

In Portugal, as in other developed countries, there has been a significant delay in reproduction in recent decades [17] relating to the second demographic transition and caused by women’s greater interest in pursuing a professional career [18], which resulted in low fertility. Thus, in 2012 the Directorate General of Health (Portugal) reported a general birth rate of 36.29 per 1000 women of childbearing age (15–49 years). Delayed childbearing has increased the proportion of births in primiparous women over 35, and the frequency of multiple deliveries due to the use of assisted reproductive technology [19]. Perinatal outcomes of pregnancies occurring after assisted reproduction techniques are known to be less successful than those following natural conception [20].

One of the first publications on Portuguese newborn characteristics was by Padez and Rocha [21] and consisted of 1232 women delivering at a small village maternity unit. Low weight at birth has also been studied using information from maternity wards to prove its adverse influence on certain diseases [22–26]. Neonatal mortality in very low birth weight deliveries has benefited from the implementation of a regionalisation policy in Portugal, which has led to the positive evolution of perinatal and neonatal mortality [27]. Descriptive studies have been published based on hospital records [3, 28–30]. The concordance among observations in public maternity wards and national records was assessed by Alves et al. [31]. A progressive downward trend in mean birth weight in Portugal in recent years was reported [32], which was attributed to shifts in the duration of gestation. Portuguese mothers over 35 years were also associated with a higher incidence of low birth weight, and with delivering a newborn of parity 1 (without previous children).

Although in Western Europe perinatal mortality has benefited by the improvement of medical care of pregnancies and proper attendance during deliveries, conducting to low mortality rates, survival at birth is expected to continue being highly influenced by sociodemographic, reproductive, and cultural factors. The present study is not addressed to quantify perinatal mortality rates (stillbirths and early neonatal). This information is available in several articles based on data in last term provided by the National Institute for Statistics of Portugal, for instance, those of Graafmans et al. [6] and Zeitlin et al. [33]. These papers provide comparable mortality rates after selecting gestations ≥28 weeks for determining stillbirth rates. The same occurs with Robalo et al. [3] report based on data from a tertiary-perinatal referral maternity. Accordingly, our paper aims to provide a first biodemographic analysis of the perinatal mortality in Portugal regarding their possible determinants in the general population, such as maternal age at delivery, child’s birth weight, and prematurity. In addition, the existence of an Iberian Peninsula pattern (Portugal plus Spain) is to be checked. Analyzing individual data on pregnancies instead of aggregated data constitutes a different approach which intends to complement the information coming from a medical perspective.

2. Materials and Methods

The information here analyzed was supplied by the Portuguese Institute of Statistics (INE). Data were not aggregated as in most overall population analysis; instead they consisted of individual digital records for each live birth and perinatal death (microdata), appearing as yearly files from 1988 to 2011. After combining births and deaths registers, a data base of 2,618,467 records was obtained (one record per pregnancy).

In Portugal the National Institute for Statistics registers foetal mortality for gestational ages of 22 weeks and more. However, in the microdata records variations were detected in the format of the yearly perinatal mortality files and in the codification of variables. Depending on the characteristics of the data the initial yearly files were grouped into three sets: 1988–1995, 1996–2009, and 2010-11. The quality of the records between 1996 and 2009 was poor (many missing cases) which made it impossible to consider certain variables such as the duration of gestation for these years.

For weight at birth the following categories were considered: 500–1499 g; 1500–2499 g; 2500–4000 g; >4000 g. For particular analysis values less than 500 grams were discarded; that was the case for a live birth of 300 grams or a new born at term of 400 g. Discarded cases are very scarce; for instance, in 2011 they were 0.0124%.

The duration of gestation in the microdata files did not appear always as quantitative variables (weeks) but categorical (merged into categories). For the years 1988–1995 and 2010-2011, some few cases in which the duration of gestation was lower than 22 weeks were discarded, and the following groups were considered: 22–31; 32–36; 37–40 and >41 weeks. For the years where the duration of gestation was unknown, mortality rates for pregnancies lasting 22 or 26 weeks or more were estimated by linear regression in order to obtain the values represented in Figure 1.

Figure 1: Yearly stillbirth and early neonatal and perinatal mortality rates (×1000) for total deliveries and gestations ≥22 and ≥26 weeks. Period 1996–2009: values of gestations ≥26 weeks estimated by linear regression on the total rates (corrected R ² = 0.998, 0.986 and 0.992, resp., for each type of mortality). For stillbirths, also gestations ≥22 weeks estimated by linear regression on the total rate (corrected R ² = 0.998).

Parity (birth order) is as follows: parity = 1 in case of a first birth (nulliparous); parity = 2 for a second or subsequent births (multiparous).

Maternal age is as follows: <20; 20–29; 30–39; 40–49 years. 179 mothers aged 50 or older were discarded as no stillbirths were found for this age group.

Once records with missing values of the variables to be analyzed were excluded, the original database reduced to 2,547,366 valid cases.

Forward (Wald) binary logistic regressions were applied, taking stillbirths and early neonatal and perinatal deaths separately as the dependent variables. Stillbirth was defined as a baby born with no signs of live while early neonatal mortality represents deaths occurring in the first seven days after delivery. Perinatal mortality is given by the sum of both types of deaths. Although the WHO recommends a threshold of 28 weeks’ gestation in order to obtain international comparable values, in the present study particular criteria of selection were applied for considering they could better reflex the interaction of maternal-foetal variables as well as discarding wrong values.

For covariables, the reference category was assigned to the group with the lowest mortality rate: type of delivery (single), sex (females), duration of gestation (37–41 weeks), birth weight (2500–4000 grams), maternity age (<20 years), and parity (2 or more). The year was taken as a quantitative variable, and the reference was the first year analysed (1988).

Due to the incompleteness of the records, two types of regressions were performed:

(a)For the period of 1988–2011, the duration of gestation and parity could not be used as covariables.(b)For years 1988–1995 and 2010-2011, duration of gestation (≥22 weeks) and parity (nulliparous-multiparous) were added as covariables.

3. Results

For the period 1988–2011, the number of total births (live and stillbirths) estimated from the microdata files was equal to 2,547,366. In Table 1 are indicated the annual numbers of stillbirths and early neonatal deaths as well as the corresponding rates per 1000 births (only live births in case of neonatal). The overall frequencies of stillbirths and early neonatal deaths were 15,944 (6.26 per 1000) and 8,256 (3.26 per 1000), respectively. The yearly number of births declined from 118,711 in 1988 to 90,557 in 2011. Throughout time rates decreased in 66.4% for stillbirths and in 70.2% for early neonatal mortality. The proportion of stillbirths to perinatal mortality was high up to 2001 where the proportion was 3.2 times larger. Since then, the proportion decreased to the half.

Table 1: Yearly frequency of stillbirths, early neonatal deaths, and total births. Rates of stillbirths and early neonatal deaths. Proportion stillbirth rate/early neonatal rate.

Year
Stillbirths
Stillbirths rate
Early neonatal
Early neonatal rate
Total births
Proportion

1988
1152
9.70
816
6.94
118711
1.40

1989
1156
10.04
724
6.35
115110
1.58

1990
1010
8.94
598
5.34
112931
1.67

1991
984
8.72
616
5.50
112897
1.58

1992
909
8.15
494
4.46
111548
1.83

1993
887
8.04
419
3.83
110345
2.10

1994
825
7.81
327
3.12
105577
2.50

1995
747
7.22
333
3.24
103490
2.23

1996
759
7.13
323
3.06
106424
2.33

1997
692
6.35
299
2.76
108937
2.30

1998
687
6.28
288
2.65
109339
2.37

1999
671
6.03
263
2.38
111270
2.54

2000
696
6.05
255
2.23
115135
2.71

2001
662
6.14
206
1.92
107809
3.19

2002
592
5.41
342
3.14
109446
1.72

2003
508
4.74
264
2.48
107159
1.92

2004
428
4.13
259
2.51
103667
1.65

2005
434
4.18
215
2.08
103781
2.01

2007
377
4.18
212
2.24
97027
1.86

2008
341
3.89
217
2.19
97913
1.77

2009
381
3.48
243
2.22
93573
1.57

2010
334
4.07
133
2.61
94936
1.56

2011
295
3.52
187
1.41
90557
2.50

Stillbirths and early neonatal deaths regardless of duration of gestation. Early neonatal deaths: under one week of life. Denominator for the stillbirth rate is equal to the sum of live births plus stillbirths. Denominator for the early neonatal mortality rate is equal to live births.

Stillbirths deserve particular attention due to their notable contribution to perinatal mortality. Thus in order to obtain rates comparable to those available for the country closest to Portugal (Spain), where compulsory inscription covers only those who are stillborn of 26 or more weeks [34], the rates were recalculated including only pregnancies of 22 or 26 weeks’ gestation. Figure 1 shows the rates corresponding to overall perinatal and early neonatal deaths (less than 7 days after delivery) and stillbirths regardless of the duration of gestation (crude rates) and for ≥26 weeks (also ≥22 weeks for stillbirths).

The annual crude stillbirth rates and the estimated rates for gestations of at least 22 or 26 weeks shown in Figure 1 indicate that the proportion of pregnancies of 26 weeks or more is 76.3% of the total stillbirth rate in 1995 and 96.92% in 2011. This figure reveals a change in trend in 2004, after which rates remained somewhat stable, at around 3 per 1000.

Table 2 shows the stillbirth rates for various categories of variables. Aside from the duration of gestation, the risk of stillbirth depends on the child’s sex. For merged data, stillbirth rates in Portugal are unfavourable for males.

Table 2: Stillbirth rates ×1000 (S.B.) by category group for each variable studied (1988–2011).

Variable
Group
Total
S.B. rate

Duration of gestation (weeks)
22–31
4887
593.820

32–36
15058
137.336

37–41
184945
13.691

>41
838
194.511

Maternal age (years)
<20
173046
4.432

20–29
1426046
4.889

30–39
1013607
6.564

40–49
62862
15.287

Birth weight (grams)
<1500
27625
227.982

1500–1249
163634
24.341

2500–4000
2323280
1.867

>4000
151848
2.127

Sex
Male
1379784
6.095

Female
1297595
5.724

Type of delivery
Single
2615518
5.711

Multiple
61968
16.266

Parity
1st
1410194
3.182

2nd or more
1259135
2.981

Marital status
In couple
1161861
3.903

Not in couple
477666
6.048

Duration of gestation: 1996–2009 is not considered. Marital status: values since 1997.

Births from multiple pregnancies are observed to be associated with more frequent stillbirths. All these groups had lower rates at the end of the period analysed, particularly in the case of multiple deliveries.

In the present study, a higher stillbirth risk was found for women who had no previous deliveries (nulliparous) than in women who had experienced maternity. The same applies for late maternities.

A priori, the duration of gestation reveals the greatest influence on that rate, followed by weight at birth. Other variables included in this table such as maternal age, parity, marital status, being born from a multiple gestation, and sex appear to play a less important role.

A set of binary logistic regressions were computed in order to model the interaction of the above variables, using the existence of a stillbirth as the dependent variable (Tables 3(a) and 3(b)).

Table 3: (a) 1988–95 and 2010-11 forward (Wald) binary logistic regression parameters. Dependent variable: stillbirths (≥500 grams regardless of duration of gestation). (b) 1988–95 and 2010-11 forward (Wald) binary logistic regression parameters. Dependent variable: stillbirths (duration of gestations ≥22 weeks).

(a)

Covariable
df
With multiple
Only single

Wald

OR
Wald

OR

Multiple (S)
1
51

0.755
—
—
—

Sex (female)
1
43

1.126
41

1.127

BW (2500–4000)
3
58051

57026

    >4000
1
206

1.933
189

1.897

    1500–2499
1
15189

16.626
14839

16.857

    <1500
1
56348

212.788
55134

217.684

Mat. age (<20)
3
2949

2804

    20–29
1
92

1.482
86

1.472

    30–39
1
993

3.711
966

3.734

    40–49
1
8

1.155
12

1.206

Year (1988)
1
3223

0.922
2884

0.925

Nagelkerke

0.312
0.309

In parentheses the reference category (S: single; BW: birth weight; weeks: duration of gestation). df = degrees of freedom; = statistical significance < 0.01. OR = relative risk. Wald values taken to the nearest integer. Nagelkerke corrected for total and single deliveries.

(b)

Covariable
df
With multiple
Only single

Wald

OR
Wald

OR

Multiple (S)
1
4

0.891
—
—
—

Sex (female)
1
4

1.055
5

1.058

BW (2500–4000)
3
6715

6379

    >4000
1
208

2.272
190

2.227

    1500–2499
1
4091

9.493
3972

9.576

    <1500
1
5880

45.880
5463

44.503

Mat. age (<20)
3
584

538

    20–29
1
11

1.171
12

1.177

    30–39
1
197

2.058
188

2.058

    40–49
1
28

0.679
25

0.686

Weeks (37–41)
3
2102

2130

    >41
1
157

2.745
162

2.807

    32–36
1
1401

3.553
1412

3.673

    22–31
1
1656

7.664
1669

8.250

Parity (>1)
1
3
ns
1.048
4
ns
1.056

Year (1988)
1
897

0.934
760

0.937

Nagelkerke

0.326
0.323

In parentheses the reference category (S: single; BW: birth weight; weeks: duration of gestation). df = degrees of freedom; = statistical significance < 0.05, < 0.01, ns nonsignificant. OR = relative risk. Wald values taken to the nearest integer. Nagelkerke corrected for total and single deliveries.

Since some studies exclude multiple deliveries from the analysis while others do not, these tables show the regression parameters with and without multiple deliveries. Due to the deficiencies in the data, this first regression does not take into account the child’s degree of maturation. The “Wald” column in the table corresponds to a statistic based on the chi square test, in which high values indicate a strong relationship between a covariable and the dependent variable. The proportion of variation explained by the model (from 0 to 1) is given by the Negelkerke R ² coefficient. According to this regression, very low birth weight represents the highest risk factor, followed at a distance by low birth weight (1500–2499 grams). The relative risk obtained from these two models is mostly unaffected by the inclusion or exclusion of multiple deliveries as a covariable. For the years 1988–95 and 2010-11, duration of gestations ≥ 22 and parity were included in the models (Table 3(b)), again considering or excluding multiple deliveries. Although the percentage of variability explained by the models (Nagelkerke R ²) is greater in the case of gestations ≥ 22 weeks, the inclusion of these two variables, mostly parity, does not substantially alter the relative importance of risks attributed to each category of variables: very low birth weight remains the highest, followed by low birth weight and very premature pregnancies. The exclusion of multiple deliveries very slightly reduces R ². The results in Table 3(b) reveal that in Portugal low weight and prematurity are the most important risk factors for stillbirth.

Early neonatal mortality denotes deaths occurring before the seventh day after delivery and, in combination with stillbirths, constitutes perinatal mortality. The distribution of the number of hours of survival in Table 4 shows that about 50% of deaths occurred during the first day of life and that no clear temporal pattern of change can be observed, although cases of survival for 72 hours increased slightly in 2010-11. The lesser contribution of early neonatal mortality to perinatal mortality over time is therefore due to an early decrease in this category of deaths, rather than to a variation in survival duration.

Table 4: Percentage of early neonatal deaths by hours of survival after delivery.

Year
Hours

<24
24–47
48–71
72–167

1988
55.710
16.975
10.185
17.130

1989
58.874
15.188
9.898
16.041

1990
60.125
13.570
9.812
16.493

1991
55.906
15.551
9.646
18.898

1992
58.495
15.049
9.223
17.233

1993
55.775
18.310
9.014
16.901

1994
52.962
11.498
14.286
21.254

1995
54.887
13.910
8.647
22.556

2010
38.889
26.389
11.111
23.611

2011
52.041
18.367
9.184
20.408

Data not available for 1996–2009.

Tables 5(a) and 5(b) show the results of the logistic regressions taking early neonatal and perinatal deaths as the dependent variable and using as factors the same set of variables and categories as for stillbirths. The values in this table fairly closely resemble the rates for stillbirths. Very low birth weight, low birth weight, and very brief pregnancies continue to be the main risk factors. Multiple deliveries show OR > 1 in contrast to stillbirths. The same considerations apply to perinatal deaths, that is, stillbirths plus early neonatal deaths.

Table 5: (a) 1988–95 and 2010-11 forward (Wald) binary logistic regression parameters. Dependent variable: early neonatal deaths. (b) 1988–95 and 2010-11 forward (Wald) binary logistic regression parameters. Dependent variable: perinatal deaths.

(a)

Covariable
df
With multiple
Only single

Wald

OR
Wald

OR

Multiple (S)
1
37

1.439
—
—
—

Sex (female)
1
69

1.312
67

1.322

BW (2500–4000)
3
3158

3030

    >4000
1
47

1.747
41

1.692

    1500–2499
1
1914

7.970
1973

8.429

    <1500
1
2852

34.038
2588

32.901

Mat. age (<20)
3
292

266

    20–29
1
1
ns
0.943
1
ns
0.947

    30–39
1
29

1.389
31

1.421

    40–49
1
117

0.335
97

0.358

Weeks (37–41)
3
1552

1463

    >41
1
135

3.177
136

3.197

    32–36
1
637

3.208
649

3.304

    22–31
1
1437

11.481
1318

11.451

Parity (>1)
1
5

0.925
3
ns
0.940

Year (1988)
1
590

0.930
503

0.930

Nagelkerke

0.336
0.312

Left, duration of gestation ≥22 weeks. In parentheses the category of reference (S: single; BW: birth weight; weeks: duration of gestation). df = degrees of freedom; = statistical significance < 0.05, < 0.01, ns nonsignificant. OR = relative risk. Wald values taken to the nearest integer. Nagelkerke corrected for total and single deliveries.

(b)

Covariable
df
With multiple
Only single

Wald

OR
Wald

OR

Multiple (S)
1
3
ns
1.084
—
—
—

Sex (female)
1
44

1.150
46

1.152

BW (2500–4000)
3
9365

8903

    >4000
1
238

2.058
252

2.100

    1500–2499
1
5854

8.899
5454

8.108

    <1500
1
8017

41.130
7701

36.051

Mat. age (<20)
3
788

848

    20–29
1
4
ns
1.076
5

1.085

    30–39
1
197

1.790
239

1.884

    40–49
1
105

0.535
83

0.577

Weeks (37–41)
3
3472

3541

    >41
1
288

2.911
289

2.915

    32–36
1
1980

3.412
1938

3.362

    22–31
1
2888

9.081
3.018

9.317

Parity (>1)
1
0
ns
1.005
57

1.184

Year (1988)
1
1384

0.932
1554

0.929

Nagelkerke

0.360
0.350

Left, duration of gestation ≥22 weeks. In parentheses the category of reference (S: single; BW: birth weight; weeks: duration of gestation). df = degrees of freedom; = statistical significance < 0.05, < 0.01, ns nonsignificant. OR = relative risk. Wald values taken to the nearest integer. Nagelkerke corrected for total and single deliveries.

4. Discussion

The frequency of stillbirths and overall early neonatal deaths decreased from 1888 to 2011 when stillbirth rates were equal to 3.52. The rates obtained from microdata (9.70 in 1988) may be compared with those reported for 1994 [6], using values for pregnancies at least 28 weeks published by the Portuguese National Institute for Statists (1996), 9.2 (8.6–9.8), as well as Eurostat Demographic Statistics (1997), 9.3 (8.7–9.8).

For pregnancies at least 28 weeks stillbirths rates of 2.69 (2.4–3.0) were reported for the year 2004 [1]. This rate was very close to that obtained after applying a birth weight criteria (at least 1000 g): 2.64 (2.3–2.9). In Portugal, as in other developed countries complications during pregnancy are few and outcomes are generally favourable for both mothers and infants [35]; stillbirths currently account for more than 50% of all perinatal deaths [36].

Although it is difficult to set a range of limit continuous variable such as foetal maturation [37], the relative contribution of stillbirths to perinatal mortality increased throughout time up to 2001 where the proportion was 3.2 times larger. After that, the proportion decreased to values over 1.5 (Table 1). Better prenatal medical following of pregnancies could explain the temporal tendency observed in the relationship between death at delivery and those along the first week of life. But also increased survival to birth may have been taken to delayed mortality occurring during the first week of life. In fact 50% of early neonatal death occurred during the first 24 hours after delivery (Table 4).

International differences in countries’ published perinatal mortality rates partly reflect the differences between each country’s criteria for registering perinatal deaths [6]. To check the existence of an Iberian perinatal mortality pattern, Figure 1 represents rates for Portugal and Spain, where compulsory inscription covers only those who are stillborn of 26 or more weeks [34]. The temporal reduction in perinatal mortality is evident irrespective of duration of gestation. However, when valid cases are restricted to longer maturation ages, the curves move nearer the x-axis. The rates shown in Figure 1 indicate a change in trend in 2004, after which rates remained somewhat stable, at around 3 per 1000. In singleton pregnancies of 26 weeks or more, Fuster et al. [34] reported stillbirth rates of 2.7 (×1000) for the years 2007–2012 in Spain, slightly lower than for Portugal (2010-2011), but in this case all type of pregnancies were considered.

Birth weight in Portugal fell between 1995 and 2011, mainly due to the higher proportion of preterm births [32]. At the same time, the proportion of multiple deliveries increased. The same phenomenon was observed for birth weight since 1980 in Spain [38]. Although the greater frequency of low birth weights and multiple deliveries in Portugal could be considered unfavourable factors for birth outcomes, the reduction in perinatal mortality can be attributed to a more efficient prevention of prenatal and neonatal mortality, leading to a greater proportion of live premature deliveries [39].

Table 2 showed 1988 to 2011 merged data that state that stillbirth rates in Portugal are more frequent for males. However, yearly rates were not systematically more elevated for males. This only happened in 14 of the 24 years studied. It has been suggested that the males’ disadvantage may be related to side effects stemming from their greater average size. Slight differences were detected in male/female who were stillborn for any factor related to survival, such as mother’s age, education, birth order, and length of gestation [40].

The more elevated stillbirth risk found for nulliparous mothers may be attributed to obstetric complications which are more frequent in first deliveries when there is a higher risk of delivering low birth weight infants and infants with restricted intrauterine growth [41]. Also, higher risk associated with late maternity could be related to a greater demand for reproductive treatments, which significantly increase the risk of stillbirths [42].

Tables 3(a) and 3(b) show that besides sex and multiple births other factors such as duration of gestation and weight at birth can be expected to relate to the risk of stillbirth. A priori, the duration of gestation reveals the greatest influence on that rate, followed by weight at birth. Other variables included in this table such as maternal age, parity, marital status, being born from a multiple gestation, and sex appear to play a less important role.

The binary logistic regressions appearing in Table 3(a) consider or ignore multiple deliveries but the child’s degree of maturation was not taken into account in this table because of lack of information. The relative risk obtained from these two models is mostly unaffected by the inclusion or exclusion of multiple deliveries as a covariable. Luke and Brown [43] reported that stillbirths have a complex multifactorial condition and are influenced by parity, weight at birth, and the duration of gestation, in addition to maternal age. For the years 1988–95 and 2010-11 the percentage of variability explained by the models (Nagelkerke R ²) is greater in the case of gestations ≥ 22 weeks; the inclusion of these two variables, mostly parity, does not substantially alter the relative importance of risks attributed to each category of variables: very low birth weight remains the highest, followed by low birth weight and very premature pregnancies. The exclusion of multiple deliveries very slightly reduces R ². The results in Table 3(b) reveal that in Portugal low weight and prematurity are the most important risk factors for stillbirth, which agrees with the findings of Mohsin et al. [9].

With regard to maternal age, a study in Italy found that adverse foetal outcomes start to accelerate after mothers reach the age of 35 and increase with age, rising more quickly from the age of 40 [10]. This is also true for Portugal, as shown in Tables 3(a) and 3(b). However, this is not as evident for mothers aged over 40 when considering relative risks from the logistic regression.

Early neonatal mortality denotes deaths occurring before the seventh day after delivery and, in combination with stillbirths, constitutes perinatal mortality. The distribution of deaths during the first seven days after birth resulted in an accumulation of cases during the first day of life (Table 4). The lesser contribution of early neonatal mortality to perinatal mortality over time is therefore due to an early decrease in this category of deaths, rather than to a variation in survival duration.

The results obtained from the logistic regression analyses indicate close patterns for stillbirths (Table 5(a)) as well as for the perinatal mortality (Table 5(b)). In both cases the set of variables included in the model to represent the main risk factors were the same: very low birth weight, low birth weight, and very brief pregnancies continue to be the principal risk factors. A difference was observed with regard to multiple deliveries which associate with increased risk in case on early neonatal mortality. Analyzing stillbirths and early neonatal mortality together gave the same results as those obtained when analyzing each of them separately.

Late childbearing in Portugal, as in most developed countries, has become predominant. This affected mostly women with an advanced education, who frequently chose voluntary postponing of pregnancies for personal or professional reasons [17]. Late childbearing also may be related to a greater demand for reproductive treatments which result in an increased stillbirth risk [42].

Concerning parity, a greater stillbirth risk was found for nulliparous women than for those who had previously had children. Obstetric complications are more frequent at first delivery for which there is a higher risk of low birth weight infants and intrauterine-growth-restriction [41].

In comparison with Spain, several papers have intended to find similitudes between the Portuguese and Spanish biodemographic patterns respecting multiple deliveries and birth weight [32, 38]. The yearly evolution of double and triple deliveries in Portugal and its territorial distribution resemble that of Spain [32, 38]. In addition, the factors determining multiple births are similar in both countries, indicating an Iberian Peninsula pattern. Differences found in recent years are consistent with a more extensive use of assisted reproductive technology cycles [44].

A higher incidence of low birth weight occurred among Portuguese mothers over 35 years. Moreover, being a newborn of parity 1, and with the mother not in a couple, resulted frequently in more low birth weight. From 1988 to 2011 there was in Portugal a progressive reduction in the average weight at birth related to changes in the duration of gestation. An initial decline in the frequency of postterm births took place, followed by small variations from 1995 on. Long gestation periods and having reached a secondary or university education constituted a favorable factor regarding birth weight [32].

With regard to stillbirths and the socioeconomic conditions, it was reported for Spain that those mothers residing in regions with high unemployment had a greater chance of stillbirth [15]. It was also found that the mother’s level of schooling was an indicator of unfavorable socioeconomic conditions. The relationship between schooling and stillbirths varies depending on maternal age. Spanish women with limited schooling (less than 5 years) show a higher risk of stillbirth than the non-Spanish. This finding is possibly related to the fact that in Spain women with less than 5 years of schooling come from very low socioeconomic segments of the population [34]. Contrarily to the studies on Spain, socioeconomic covaribles such as the marital status and the mothers’ education were not included in the models for Portugal. Moreover, multiple pregnancies did not appear as determinant for stillbirths. However, early neonatal mortality showed a certain influence. Very low birth weight and maternal ages older than 30 and short gestations (for the years with available data) appeared as significant factors explaining the risk both of stillbirth or neonatal mortality.

5. Conclusion

Regardless of the model applied in this analysis, a relative risk (R.R) < 1 was always found for the year. This agrees with the temporal variation shown in Figure 1 and consists of a rapid initial decrease followed by a steady variation in subsequent years. This recalls the results reported by Gregory et al. [45] in the United States, where after declining from 2000–2006 overall (≥20 weeks), early (20–27 weeks), and late (≥28 weeks) foetal mortality rates remained essentially unchanged for 2006–2012. Although the situation in the labour market may have negatively affected the unemployed population [46], improvements in medical neonatology should have been sufficient to maintain low levels of perinatal mortality.

In a Portuguese retrospective analysis of 208 singleton stillbirths delivered in a tertiary-perinatal referral maternity unit over a 10-year period (2000–2009), Robalo et al. [3] found that the primary cause of death was foetal, and there was no temporal change in the incidence of late stillbirth. The change described here for Portugal is explained by the fact that the country’s perinatal care was reformed in 1989 in order to coordinate local health centres and hospitals [47]. A national system was set up for neonatal transport to hospital maternity units (levels II and III), in addition to postgraduate courses on neonatology. After this reform, hospital deliveries became practically universal, and perinatal mortality decreased substantially. This is consistent with the situation observed in most western European countries as shown by the EUROSTAT databases [48], where in 2011 Portugal shows late foetal and early neonatal mortality rates below the European Union (28 countries) average and close to the values for Spain, Italy, and Greece. Although at present in Portugal the perinatal mortality is very low, multiple logistic regressions show that low birth weight (<1500 g) and maternal ages older than 30 and gestations <31 weeks remain the main factors determining the risk of a stillbirth or a neonatal death. The application of different criteria for selecting cases (multiple-singletons; minimum birth weight or minimum duration of gestation) does not modify significantly the above models. Certain similarities with the factors determining negative birth outcomes in Spain are appreciated. Regarding population preventive politics particular attention should be addressed to mothers older than 30 delivering children of low or very low birth weight or premature or extreme premature. No risk associated to nulliparity was found in this study.

Competing Interests

The author declares that there is no conflict of interests regarding the publication of this paper.

Acknowledgments

The author would like to thank Dr. Carlota Santos, History of Populations Group/CITCEM, Department of History-Institute of Social Sciences, Minho University, Braga, Portugal, for her intermediation with the Portuguese Institute of Statistics in order to obtain the data. This study has been partly supported by Project CGL2008-03737 (Spain).

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