The 1918-19 influenza pandemic in Boyaca, Colombia.
Influenza viruses (Health aspects)
Aged (Health aspects)
Epidemics (Development and progression)
Epidemics (Health aspects)
Swine influenza (Development and progression)
Swine influenza (Health aspects)
Disease susceptibility (Development and progression)
Disease susceptibility (Health aspects)
Disease transmission (Development and progression)
Disease transmission (Health aspects)
Miller, Mark A.
Diaz, Juan M. Ospina
Martinez-Martin, Abel Fernando
|Publication:||Name: Emerging Infectious Diseases Publisher: U.S. National Center for Infectious Diseases Audience: Academic; Professional Format: Magazine/Journal Subject: Health Copyright: COPYRIGHT 2012 U.S. National Center for Infectious Diseases ISSN: 1080-6040|
|Issue:||Date: Jan, 2012 Source Volume: 18 Source Issue: 1|
|Product:||Product Code: 8000120 Public Health Care; 9005200 Health Programs-Total Govt; 9105200 Health Programs NAICS Code: 62 Health Care and Social Assistance; 923 Administration of Human Resource Programs; 92312 Administration of Public Health Programs|
|Geographic:||Geographic Scope: Taiwan; Colombia; Mexico Geographic Code: 9TAIW Taiwan; 3COLO Colombia; 1MEX Mexico|
Quantitative analyses of age-specific death rates,
transmissibility, and dissemination patterns of the 1918 influenza
pandemic in the United States (1,2), Mexico (3), Peru (4), Japan (5),
Europe (6,7), Taiwan (8), and Singapore (9) have shed light on the
epidemiology of the most devastating pandemic in recent history (10).
These studies revealed the pandemic's unusual severity in young
adults, occurrence in multiple waves, and higher transmission potential
than that of seasonal epidemics (11). However, quantitative historical
studies remain scarce for Latin America, Africa, and Asia, where our
understanding of influenza disease patterns remains particularly weak.
The emergence of the pandemic influenza A (H1N1) 2009 virus in Mexico (12,13) reinforced the need to understand the epidemiology of past pandemics in the Americas to inform preparedness plans. We therefore analyzed death patterns for the 1918 influenza pandemic in Boyaca, a rural area in central Colombia, where influenza seasonality is less defined than in temperate regions (14). By using archival records, we quantified the age-specific excess-death rates and transmission potential of the 1918-19 pandemic in Boyaca and compared these findings with those reported for other locations, especially Mexico City, Mexico.
Materials and Methods
Boyaca is located in the central part of Colombia within the Andes Mountains at latitude [approximately equal to] 5.5[degrees]N (Figure 1). In 1918, the population of Boyaca was 659,947 and <50% of the area was occupied. Hygienic conditions were poor. A centralized disease notification system was lacking; however, death records were maintained by parishes.
The climate in Boyaca varies from high humidity and high mean temperature ([approximately equal to] 40[degrees]C) in low areas near the Magdalena River (altitude 600 m) to cold mean temperature (<6[degrees]C) and permanent snow in the Cocuy Mountains (altitutde 5,500 m). The 2 rainy seasons, April-May and October-November, produce [approximately equal to] 1,000 [mm.sup.3]/rainfall/year.
Historical Death Records
A total of 32,843 death records, written mostly by Catholic priests and corresponding to January 1917-December 1920, were manually retrieved from the parish archives of 78 municipalities in the department of Boyaca. From these archival records, we extracted age, cause, and exact date of death. To estimate mortality rates, we compiled weekly numbers of deaths from all causes and from respiratory illness, stratified into 5-year age groups (Figures 2, 3). To obtain precise estimates of the transmission potential, we compiled daily death time series, combining all age groups.
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We obtained age-specific estimates of population size for the department of Boyaca from a 1918 census report (15). In 1918, [approximately equal to] 70% of Boyaca's population was located in rural areas. During 1912-1918, the average annual population growth rate in Boyaca was 1.7%; during 1918-1920, it was 3.8%.
Estimation of Excess Deaths
For characterization of mortality rates for the Boyaca pandemic, influenza-associated mortality rates must be separated from background mortality rates (deaths from respiratory illness other than influenza) and considered separately for each age group and cause of death (respiratory or all causes). To estimate pandemic mortality rate, we can define a discrete period of pandemic influenza activity and estimate the number of deaths in excess of background deaths that occurred during the pandemic period. Because mortality rates tend to vary seasonally throughout the year, our background estimate must also vary seasonally. To find the best estimate for baseline mortality rate in the absence of influenza activity, we applied regression methods, using harmonic terms and time trends, to mortality rate data (6,16,17) (online Technical Appendix, wwwnc.cdc.gov/ EID/pdfs/10-1969-Techapp.pdf ).
The regression model determines the extent to which observed weekly mortality rate fit the expectation of background mortality rate. Periods of poor fit indicate that observed mortality rate exceeds typical baseline levels, presumably because of increased influenza activity.
We defined pandemic periods as the weeks when deaths from respiratory illness exceeded the upper limit of the 95% CI of the background model. To estimate the mortality rate during the pandemic, for each age group we summed the weekly number of deaths from respiratory illness and from all causes that exceeded model baseline rates during each pandemic period during 1918-20.
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To ensure that our estimates were not sensitive to modeling assumptions, we also estimated excess deaths by using an alternative approach to calculate background deaths. In this approach, background mortality rates for a given week are obtained by averaging mortality rates during the same week in previous years (online Technical Appendix).
Finally, we estimated a relative measure of the effects of pandemic-associated deaths for each age group, which considers the typical mortality rate experienced by that age group. We calculated relative risk for pandemic-associated death, defined as the ratio of excess deaths during pandemic periods to expected baseline deaths. Relative risk has been shown to facilitate comparison between age groups or countries, which have different background risks for death (17,18).
Comparing Patterns of Age-specific Deaths
We compared patterns of age-specific excess deaths from the 1918-19 Boyaca pandemic with those recently published for Mexico City (3). The estimates for Mexico City were based on excess-death rates obtained from monthly pneumonia and influenza records (1916-1920), stratified by 6 age groups (<5, 5-19, 20-29, 30-49, 50-69, and [greater than or equal to] 70 years). Excess-death rates for Mexico City were calculated with a method similar to that used in this study.
We also reviewed key epidemiologic features of the pandemic in various locations as recently reported (1,3,4,6-9,19,20), focusing on comparisons of overall excess-death rates associated with the pandemic. We also reviewed epidemiologic evidence for early (herald) waves occurring before September 1918 and for death sparing among elderly persons. We limited the review to studies that provided monthly or weekly historical death data because such data enable identification of herald waves and precise estimation of excess-death rates.
Estimation of Transmission Potential
Transmissibility of an infectious pathogen is measured by the basic reproduction number (R0), which is the average number of secondary infections generated by an infectious person in an entirely susceptible population (21). A related quantity is the reproduction number, R, which can be used for partially immune populations who have been vaccinated or previously exposed to similar pathogens (21).
We estimated R for the 1918 pandemic virus in Boyaca by using a simple method that relies on the epidemic growth rate, a measure of how fast the number of cases increases over time (online Technical Appendix). Briefly, in the early ascending phase of an epidemic, the daily number of cases (or deaths) should follow an exponential function. By taking the log of daily deaths in the ascending phase, a straight line can be fit to the data. R can be derived from the growth rate estimate r by a simple equation involving the duration of the latency and infectious periods (22) (online Technical Appendix).
Because of the uncertainty associated with duration of the latency and infectious periods for influenza, we considered periods of 1.5 and 2 days each (23,24). Latency and infectious periods can be summed into a single statistic called the generation interval, which measures the interval between disease onset in 2 successive cases. The generation intervals considered in this study were 3 and 4 days (23,24).
We defined the ascending phase as the period between the day of pandemic onset (defined as the first day of the period of steadily increasing deaths) and the day immediately before the epidemic peak. We tested the robustness of R estimates to the choice of death indicator (deaths from respiratory illness or from all causes). We also compared estimates derived from crude numbers of deaths and excess deaths from respiratory illness that were above background rates.
The same approach and assumptions have been used to quantify Rs associated with the 1918 pandemic in Copenhagen, Denmark, and Mexico City, and hence the Boyaca estimates are directly comparable to estimates from these studies (3,6). For comparison with Boyaca, we also reviewed the literature for published estimates of R associated with the 1918 pandemic in the Americas (2-4).
Timing of Pandemic Waves and Age-specific Patterns of Death
The age-stratified time series of deaths from respiratory illness or all causes in Boyaca indicated that a severe pandemic wave occurred during a 15-week period, October 20, 1918-January 26, 1919 (Figures 2, 3). The profile of age-specific excess deaths from respiratory illness associated with the pandemic period formed a W-shaped pattern; peak mortality rates among infants (<5 years of age) were followed by peak rates among elderly persons (>60 years) and young adults (25-29 years) (Table 1). Excess deaths were lowest among children 5-14 years of age and adults 50-59 years of age. Similar age patterns were found for all-cause deaths (Figure 4); the correlation coefficient between respiratory and all-cause excess-death rates was >0.99 (p<0.01). Excess deaths from respiratory illness captured most influenza-related all-cause excess deaths across all age groups (95% on average, range 81%-100%). Confidence intervals were larger for the most extreme age groups.
To facilitate the comparison between population age groups with different background risks for death, we calculated the risk for excess-death rates relative to baseline rates (Table 1). Although absolute excess-death rates were highest for young children (0-4 years of age) and elderly persons ([greater than or equal to] 60 years), during the pandemic the relative risks were lowest for these age groups. Relative risk was highest for young adults 25-29 years of age; excess-death rates increased 51-fold above background death rates for respiratory causes and 6-fold for all causes.
[FIGURE 4 OMITTED]
Comparison of Boyaca and Mexico City shows that age-specific excess-death rates produced a W-shaped pattern for both locations (Figure 5). However, excess-death rates among young adults (20-29 years) were substantially higher for Mexico City than for Boyaca. By contrast, excess-death rates among infants were 2-fold lower for Mexico City than for Boyaca. Excess-death rates for elderly persons were similar for both cities. Overall, we estimate that the October 1918-January 1919 pandemic period was associated with 47 and 40 excess respiratory deaths per 10,000 population in Mexico City and Boyaca, respectively.
[FIGURE 5 OMITTED]
A broader comparison of epidemiologic patterns associated with the pandemic at 12 locations on different continents highlights substantial variations in the timing, number of pandemic waves, and age-specific death rates (Table 2). Europe and the United States generally experienced herald waves in during March-August 1918 (except for Paris) and low excess-death rates among elderly populations. In contrast, there was no evidence of death sparing among elderly populations in Latin America or Asia, and herald waves occurred at 4 of the 7 locations studied in these regions. Excess-death rates from respiratory illness were high for Iquitos, Peru; Toluca, Mexico; and Basque Provinces, Spain (121-288 deaths/10,000 population); intermediate in Taiwan (78-180 deaths/10,000 population); and lower elsewhere, including in Boyaca (29-67 deaths/10,000 population).
Reproduction Number Estimates
Table 3 provides summary estimates for the R for the 1918 influenza pandemic in Boyaca, based on growth in daily rates for death from respiratory illness. R was estimated to be 1.4, assuming a short generation interval of 3 days, and 1.5-1.6, assuming a longer interval of 4 days. A sensitivity analysis, based on excess deaths from respiratory illness occurring above a background of expected deaths, generated slightly higher R estimates (1.4-1.5 for a generation interval of 3 days and 1.6-1.7 for a generation interval of 4 days). Different approaches for estimating background deaths resulted in R estimate differences of <0.06 (4%).
Comparison of estimates derived from different locations in the Americas revealed some geographic variations in the transmission potential of the 1918-19 pandemic wave (Table 4). Although R estimates were 1.3-1.8 in most locations in the Americas, assuming a 3-day generation interval, the transmissibility of influenza during the autumn wave might have been particularly high in Toluca, Mexico (estimated R = 2.0-2.5).
Our study makes use of extensive archival death records covering before and during the 1918-19 influenza pandemic in Boyaca, Colombia, and confirms the substantial number of deaths caused by the pandemic in this region. The main epidemiologic features of the pandemic in Boyaca include a single wave of excess deaths during October 1918-January 1919; high excess-death rates among infants and elderly persons; and a moderate R (estimated at 1.4-1.5, assuming a 3-day generation interval).
We did not identify a herald wave of deaths from pandemic influenza in the early part of 1918 in Boyaca. According to epidemiologic data, herald waves of mild pandemic activity have been reported for the spring and summer of 1918 in other regions of the world, including New York City (1), Mexico (3), Lima (4) Geneva (25,26), Copenhagen (6), military camps in the United States (6), the United Kingdom (27), and Singapore (9). The absence of a herald wave in Boyaca could be explained by late introduction of the pandemic influenza virus; alternatively, a mild first wave may have occurred without causing many deaths. Thus, we cannot rule out early pandemic activity, which might have been associated with mild illnesses, before October 1918 in Boyaca. For instance, the summer pandemic wave of 1918 in Denmark was clearly evident only from time-series case data (6). These epidemiologic findings suggesting early pandemic virus activity have recently been confirmed by sequencing of pandemic influenza virus specimens isolated from Army camp populations in the United States as early as May 1918 (28).
Although substantial postpandemic waves have been reported for 1919-20 in New York City (1), Mexico City (3), Lima (4), Japan (5), and Taiwan (8), we could not identify a clear recrudescent pandemic wave in 1920 in Boyaca. A 3-week period in January 1920 and a 4-week period in April-May 1920 were associated with a small increase in deaths from respiratory illness, mostly affecting elderly persons, but we cannot with certainty attribute these deaths to pandemic influenza. Early public health warnings and effective implementation of control interventions in large cities such as New York City, Mexico City, Lima, and Taiwan, could have contributed to maintaining a large pool of susceptible persons, which could fuel subsequent pandemic waves (29). In Japan, postpandemic waves were somewhat limited to regions that escaped earlier waves (5). Given that Boyaca was a relatively small rural area, pandemic activity in 1918 might have proceeded unabated, with no particular interventions, medical or nonmedical. Alternatively, Boyaca could have escaped the recrudescent pandemic wave in 1920 because of its remote location. Overall, the main wave of deaths from pandemic influenza that occurred during October 1918-January 1919 in Boyaca is reminiscent of the single wave of pandemic influenza A (H1N1) 2009 wave that occurred in the Southern Hemisphere during the winter of 2009 (e.g., Chile , Australia , and New Zealand ). Additional data from the 1918 pandemic in other Southern Hemisphere locations are warranted before these findings can be generalized.
The W-shaped age-specific pattern of deaths during the 1918-19 pandemic wave in Boyaca is in agreement with recent reports from the Mexico City area (3) and Peru (4). These reports suggest a lack of death sparing among elderly populations of urban and rural areas of Latin America, although data from additional locations would be useful for generalizing these conclusions. This pattern is also in agreement with anecdotal evidence from aboriginal populations in Alaska in 1918 (32). In contrast to reports for Latin America and Alaska, reports for the United States and Europe suggest that elderly populations were substantially protected from influenza-associated death in 1918 (1,5,6). Previous studies have hypothesized that childhood exposure to influenza A (H1N1) viruses before 1870 might account for prior immunity among elderly persons during the 1918 pandemic. A similar phenomenon has been noted for pandemic (H1N1) 2009, during which risk for clinical infection and death was lower during the pandemic than during seasonal epidemics for persons >60 years of age (13,33).
Regional differences in prior immunity to influenza might result from heterogeneous circulation of influenza viruses during the 19th century, when long-distance travel was much less common than it is today (3). In 1918, Colombia's population of 5.8 million was heterogeneously distributed and relatively isolated from the rest of the world (34); this isolation could explain the lack of exposure to influenza viruses during the middle of the 19th century. Also in 1918, transportation was underdeveloped in Colombia, consisting mostly of horse- or mule-drawn street cars, waterways, and sparse railroads that did not connect with Boyaca (34). Remoteness could have affected the probability of introduction and of local dissemination of influenza viruses in the Boyaca region. A similar phenomenon could also explain the apparent lack of a herald pandemic wave in the spring of 1918, when pandemic virus activity was not yet globally widespread. Of note, the capital city, Bogota, was the first area in Colombia to report increased influenza activity in October 1918; the virus quickly spread to other Colombia locations (34).
Excess-death rates among young adults were lower in Boyaca than in Mexico City (3). The reasons for this difference are unclear but could be associated with a more sporadic distribution of the population in Boyaca, resulting in lower overall influenza attack rates; however, we do not have epidemiologic evidence to support this assumption. Alternatively, the unidentified factors that made young adults particularly susceptible to influenza-related death in Europe, the United States, and Mexico in 1918 (1,5,6) might have been less common among young adults in Colombia. Despite these geographic differences in absolute risk for death from pandemic influenza, in all locations with sufficient data the relative risk for death consistently peaked among adults 20-29 years of age when compared with baseline death rates during nonpandemic years. Hence, our study confirms the universal atypical severity of this virus in young adults, as previously reported for the United States (1), Mexico (3), Europe (6,7), and Taiwan (8). We also note that data from Boyaca and Mexico City do not support the pessimistic hypothesis that populations lacking prior immunity to the 1918 virus would experience a V-shaped age-associated risk for death, in which risk would rapidly and continuously rise past teenage years (35).
Our excess-deaths approach warrants some caveats. The regression model used to estimate background deaths poorly fit the Boyaca data during the nonpandemic period, probably because of weak seasonality. However, our estimates of excess deaths from pandemic influenza based on deaths from respiratory illness and all causes were highly correlated, similar to those from other temperate countries, where baseline death rates are more seasonal (1,3,6). The sensitivity analysis that we conducted by using an alternative approach to estimate background deaths did not make assumptions about seasonality (20). This analysis produced excess-death estimates highly correlated with those derived from the regression approach (correlation = 0.97; p<0.01; mean difference 4%-7%).
Transmissibility estimates derived from 1918-20 pandemic illness and death data are 1.5-5.4 for community-based settings in several regions of the world (2,6,36,37) (Table 4). Our transmissibility estimates for Boyaca, Colombia, assuming a generation interval of 3 days, are in close agreement with those reported for the wave in autumn in Mexico City (3), Lima (4), England and Wales (27), and Copenhagen (6) and slightly lower than estimates reported for the city of Toluca, Mexico (3), and US cities (2,38). Boyaca's sparsely distributed population could explain why the estimated disease transmissibility is relatively low. It remains unclear whether differences in reproduction number estimates across locations and pandemic waves reflect true differences attributable to variation in attack rates or local factors affecting transmission or merely illustrate difficulties in measuring this parameter with precision (38). In previous studies focused on reproduction number estimates in which we used similar data and approaches, we have shown that inclusion of a delay between disease onset and death has little effect on the estimates (39).
In conclusion, historical studies from understudied areas are especially helpful for documenting the global death rates and transmission patterns of the 1918 pandemic and for revealing substantial variations among locations. In particular, the lack of death sparing for elderly persons in Colombia and Mexico differs markedly from contemporaneous observations in the United States and Europe. During the 19th century, the Latin American region was relatively isolated (and still is today) (40), which would affect the circulation of historical influenza viruses and baseline population immunity to influenza. We believe that this finding suggests recycling of influenza viruses as the best explanation for death sparing among elderly persons in the United States and Europe in 1918. Preservation and interpretation of archival epidemiologic data are crucial for a better understanding of past pandemics and for better preparedness against future pandemics.
We thank Tanya Wilcox for editorial assistance.
This research was conducted in the context of the Multinational Influenza Seasonal Mortality Study, which is an ongoing international collaborative effort for understanding influenza epidemiological and evolutionary patterns, and which is led by the Fogarty International Center, National Institutes of Health (www.origem.info/misms/index.php). Funding for this project comes in part (to L.S.) from the Research and Policy for Infectious Disease Dynamics program of the Science and Technology Directorate, Department of Homeland Security and Fogarty International Center, and from the Office of Global Affairs, International Influenza Unit, in the Office of the Secretary of the Department of Health and Human Services.
Dr Chowell is an associate professor in the School of Human Evolution and Social Change at Arizona State University and a research fellow at the Fogarty International Center, National Institutes of Health. His research interests include mathematical and statistical modeling of infectious disease transmission and control interventions, with a focus on seasonal and pandemic influenza and quantitative characterization of past influenza pandemics.
(1.) Olson DR, Simonsen L, Edelson PJ, Morse SS. Epidemiological evidence of an early wave of the 1918 influenza pandemic in New York City. Proc Natl Acad Sci U S A. 2005;102:11059-63. doi:10.1073/ pnas.0408290102
(2.) Mills CE, Robins JM, Lipsitch M. Transmissibility of 1918 pandemic influenza. Nature. 2004;432:904-6. doi:10.1038/nature03063
(3.) Chowell G, Viboud C, Simonsen L, Miller MA, Acuna-Soto R. Mortality patterns associated with the 1918 influenza pandemic in Mexico: evidence for a spring herald wave and lack of preexisting immunity in older populations. J Infect Dis. 2010;202:567-75. doi:10.1086/654897
(4.) Chowell G, Viboud C, Simonsen L, Miller MA, Hurtado J, Soto G, et al. The 1918-1920 influenza pandemic in Peru. Vaccine. 2011;29(Suppl 2):B21-6. doi:10.1016/j.vaccine.2011.02.048
(5.) Richard SA, Sugaya N, Simonsen L, Miller MA, Viboud C. A comparative study of the 1918-1920 influenza pandemic in Japan, USA and UK: mortality impact and implications for pandemic planning. Epidemiol Infect. 2009;137:1062-72. doi:10.1017/S0950268809002088
(6.) Andreasen V, Viboud C, Simonsen L. Epidemiologic characterization of the 1918 influenza pandemic summer wave in Copenhagen: implications for pandemic control strategies. J Infect Dis. 2008;197:270-8. doi:10.1086/524065
(7.) Erkoreka A. The Spanish influenza pandemic in occidental Europe (1918-1920) and victim age. Influenza Other Respi Viruses. 2010;4:81-9.
(8.) Hsieh YH. Excess deaths and immunoprotection during 1918-1920 influenza pandemic, Taiwan. Emerg Infect Dis. 2009;15:1617-9.
(9.) Lee VJ, Chen MI, Chan SP, Wong CS, Cutter J, Goh KT, et al. Influenza pandemics in Singapore, a tropical, globally connected city. Emerg Infect Dis. 2007;13:1052-7.
(10.) Morens DM, Taubenberger JK, Harvey HA, Memoli MJ. The 1918 influenza pandemic: lessons for 2009 and the future. Crit Care Med. 2010 Apr;38(4 Suppl):e10-20.
(11.) Miller MA, Viboud C, Balinska M, Simonsen L. The signature features of influenza pandemics-implications for policy. N Engl J Med. 2009;360:2595-8. doi:10.1056/NEJMp0903906
(12.) Fraser C, Donnelly CA, Cauchemez S, Hanage WP, Van Kerkhove MD, Hollingsworth TD, et al. Pandemic potential of a strain of influenza A (H1N1): early findings. Science. 2009;324:1557-61. doi:10.1126/science.1176062
(13.) Chowell G, Bertozzi SM, Colchero MA, Lopez-Gatell H, Alpu che-Aranda C, Hernandez M, et al. Severe respiratory disease concurrent with the circulation of H1N1 influenza. N Engl J Med. 2009;361:674-9. doi:10.1056/NEJMoa0904023
(14.) Viboud C, Alonso WJ, Simonsen L. Influenza in tropical regions. PLoS Med. 2006;3:e89. doi:10.1371/journal.pmed.0030089
(15.) Departamento de Boyaca, Colombia, Departamento Administrativo Nacional de Estadistica. Censo de 1918. Boyaca (Colombia): The Department; 1918.
(16.) Serfling RE. Methods for current statistical analysis of excess pneumonia-influenza deaths. Public Health Rep. 1963;78:494-506. doi:10.2307/4591848
(17.) Viboud C, Grais RF, Lafont BA, Miller MA, Simonsen L. Multinational impact of the 1968 Hong Kong influenza pandemic: evidence for a smoldering pandemic. J Infect Dis. 2005;192:233-48. doi:10.1086/431150
(18.) Serfling RE, Sherman IL, Houseworth WJ. Excess pneumonia-influenza mortality by age and sex in three major influenza A2 epidemics, United States, 1957-58, 1960 and 1963. Am J Epidemiol. 1967;86:433-41.
(19.) Erkoreka A. Spanish influenza in the heart of Europe. A study of a significant sample of the Basque population. Gesnerus. 2008;65:30 41.
(20.) Murray CJ, Lopez AD, Chin B, Feehan D, Hill KH. Estimation of potential global pandemic influenza mortality on the basis of vital registry data from the 1918-20 pandemic: a quantitative analysis. Lancet. 2006;368:2211-8. doi:10.1016/S0140-6736(06)69895-4
(21.) Anderson RM, May RM. Infectious diseases of humans. Oxford (UK): Oxford University Press; 1991.
(22.) Wallinga J, Lipsitch M. How generation intervals shape the relationship between growth rates and reproductive numbers. Proc Biol Sci. 2007;274:599-604. doi:10.1098/rspb.2006.3754
(23.) Ferguson NM, Cummings DA, Fraser C, Cajka JC, Cooley PC, Burke DS. Strategies for mitigating an influenza pandemic. Nature. 2006;442:448-52. doi:10.1038/nature04795
(24.) Cauchemez S, Carrat F, Viboud C, Valleron AJ, Boelle PYA. Bayesian MCMC approach to study transmission of influenza: application to household longitudinal data. Stat Med. 2004;23:3469-87. doi:10.1002/sim.1912
(25.) Ammon CE. Spanish flu epidemic in 1918 in Geneva, Switzerland. Euro Surveill. 2002;7:190-2.
(26.) Chowell G, Ammon CE, Hengartner NW, Hyman JM. Estimation of the reproductive number of the Spanish flu epidemic in Geneva, Switzerland. Vaccine. 2006;24:6747-50. doi:10.1016/j.vaccine. 2006.05.055
(27.) Chowell G, Bettencourt LM, Johnson N, Alonso WJ, Viboud C. The 1918-1919 influenza pandemic in England and Wales: spatial patterns in transmissibility and mortality impact. Proc Biol Sci. 2008;275:501-9. doi:10.1098/rspb.2007.1477
(28.) Sheng Z-M, Chertow DS, Ambroggio X, McCall S, Przygodzki RM, Cunningham RE, et al. Autopsy series of 68 cases dying before and during the 1918 influenza pandemic peak. Proc Natl Acad Sci U S A. 2011 ;108:16416-21.
(29.) Hsieh YH, Chan CH. Excess healthcare burden during 1918-1920 influenza pandemic in Taiwan: implications for post-pandemic preparedness. BMC Public Health. 2011;11:41.
(30.) Ministerio de Salud de Chile. Situacion de influenza A(H1N1). Reporte 01/26/2010 [cited 2010 Feb 15]. http://www.pandemia.cl/ index.php?id=61
(31.) ANZIC Investigators, Webb S, Pettila V, Seppelt I, Bellomo R, Bailey M, et al. Critical care services and 2009 H1N1 influenza in Australia and New Zealand. N Engl J Med. 2009;361:1925-34. doi:10.1056/NEJMoa0908481
(32.) Crosby AW. Epidemic and peace, 1918. Westport (CT): Greenwood Press; 1976.
(33.) Vaillant L, La Ruche G, Tarantola A, Barboza P. Epidemiology of fatal cases associated with pandemic H1N1 influenza 2009. Euro Surveill. 2009;14:pii:19309.
(34.) Ospina Diaz JM, Martinez Martin AF, Herran Falla OF. Impact of the flu pandemic of 1918-1919 on the general mortality profile in Boyaca, Colombia [in Spanish]. Hist Cienc Saude Manguinhos. 2009;16:53-81. doi:10.1590/S0104-59702009000100004
(35.) Palese P. Influenza: old and new threats. Nat Med. 2004;10(Suppl):S82-7. doi:10.1038/nm1141
(36.) Vynnycky E, Trindall A, Mangtani P. Estimates of the reproduction numbers of Spanish influenza using morbidity data. Int J Epidemiol. 2007;36:881-9. doi:10.1093/ije/dym071
(37.) White LF, Pagano M. Transmissibility of the influenza virus in the 1918 pandemic. PLoS ONE. 2008;3:e1498. doi:10.1371/journal. pone.0001498
(38.) Chowell G, Nishiura H, Bettencourt LM. Comparative estimation of the reproduction number for pandemic influenza from daily case notification data. J R Soc Interface. 2007;4:155-66. doi:10.1098/ rsif.2006.0161
(39.) Chowell G, Viboud C, Simonsen L, Miller M, Alonso WJ. The reproduction number of seasonal influenza epidemics in Brazil, 19962006. Proc Biol Sci. 2010;277:1857-66.
(40.) Russell CA, Jones TC, Barr IG, Cox NJ, Garten RJ, Gregory V, et al. The global circulation of seasonal influenza A (H3N2) viruses. Science. 2008;320:340-6. doi:10.1126/science.1154137
Author affiliations: Arizona State University, Tempe, Arizona, USA (G. Chowell); National Institutes of Health, Bethesda, Maryland, USA (G. Chowell, C. Viboud, M.A. Miller); George Washington University, Washington, DC, USA (L. Simonsen); Universidad Nacional Autonoma de Mexico, Delegacion Coyoacan, Mexico (R. Acuna-Soto); and Universidad Pedagogica y Tecnologica de Colombia, Boyaca, Colombia (J.M. Ospina Diaz, A.F. Martinez-Martin)
Address for correspondence: Gerardo Chowell, Arizona State University, School of Human Evolution and Social Change, Box 872402, Tempe, AZ 85282, USA; email: firstname.lastname@example.org
Table 1. Age-specific excess-death rates associated with the October 1918 -January 1919 influenza pandemic wave in Boyaca, Colombia * Deaths from respiratory illness Relative risk/ Excess mortality background rate/10,000 mortality rate Age group, y population (95% CI) ([dagger]) All ages 40.1 (39.1-41.1) 5.2 0-4 118.1 (111.1-125.1) 3.0 5-9 21.1 (20.1-23.1) 13.5 10-14 19.1 (18.1-20.1) 11.4 15-19 28.1 (27.1-30.1) 13.4 20-24 32.1 (30.1-33.1) 12.6 25-29 36.1 (34.1-37.1) 51.3 30-39 37.1 (35.1-38.1) 6.9 40-49 36.1 (33.1-39.1) 11.8 50-59 35.1 (31.1-40.1) 11.5 60-69 73.1 (67.1-80.1) 4.1 70-79 83.1 (69.1-98.1) 3.4 >80 100.1 (81.1-120.1) 3.5 Deaths from all causes Relative risk/ Excess mortality background rate/10,000 mortality rate Age group, y population (95% CI) ([dagger]) All ages 42.1 (39.1-44.1) 1.7 0-4 118.1 (109.1-127.1) 1.3 5-9 26.1 (23.1-29.1) 3.6 10-14 18.1 (16.1-20.1) 3.2 15-19 27.1 (24.1-30.1) 3.3 20-24 35.1 (31.1-38.1) 3.5 25-29 42.1 (39.1-45.1) 5.7 30-39 39.1 (36.1-42.1) 2.2 40-49 36.1 (31.1-41.1) 1.6 50-59 27.1 (19.1-35.1) 1.3 60-69 69.1 (55.1-82.1) 1.1 70-79 82.1 (59.1-106.1) 0.9 >80 124.0 (87.2-160.8) 0.9 * Excess death estimates are based on observed mortality rates during pandemic weeks occurring in excess of background mortality rates derived from a seasonal regression model. ([dagger]) Ratio of excess deaths divided by background deaths during influenza pandemic weeks, facilitating comparisons across age groups with different background risks for death. Table 2. Main epidemiologic features of the 1918-1920 influenza pandemic * Excess mortality rate from respiratory illness/10,000 population, main 1918-19 wave (mo of peak Herald wave pandemic deaths, Location in 1918 1918) Americas New York, USA Yes (Mar-Apr) 52 (Oct-Nov) Mexico City, Mexico Yes (May) 47 (Nov) Toluca, Mexico Yes (May) 162 (Nov) Boyaca, Colombia No 40 (Nov) Lima, Peru Yes (Sep-Oct) 29 (Nov) ([dagger]) Iquitos, Peru No 288 (Nov) Europe Copenhagen, Denmark Yes (Jul-Aug) 39 (Nov) Paris, France No 61 (Oct) Basque Provinces, Spain Yes (Jun) 121 (Oct) Madrid, Spain Yes (Jun) 53 (Oct) Asia Taiwan No 67 (Nov) Singapore Yes (Jul) 78-180 (Oct) Death-sparing effect among elderly Location persons Reference Americas New York, USA Yes (1) Mexico City, Mexico No (3) Toluca, Mexico No (3) Boyaca, Colombia No This study Lima, Peru Not (4) Iquitos, Peru ND (4) Europe Copenhagen, Denmark Yes (6) Paris, France ND (7) Basque Provinces, Spain ND (19) Madrid, Spain Yes (7) Asia Taiwan No (8,20) Singapore ND (9,20) * Data from quantitative studies across different locations around the world. Locations are organized by continent (America, Europe, Asia) and latitude. ND, not determined. ([dagger]) Cannot conclude because of lack of age-specific population data. Table 3. Estimates of the growth rate and reproduction number associated with the 1918-19 influenza pandemic in Boyaca, Colombia * Early growth Daily growth phase period, rate, mean Mortality outcome 1918 (95% CI) Deaths from respiratory Oct 13-Nov 15 0.121 illness (0.120-0.122) Excess deaths from Oct 27-Nov 15 0.137 respiratory illness (0.136-0.139) R estimate, mean (95% CI) 3-d generation interval Mortality outcome Exp dist. Delta dist. Deaths from respiratory 1.40 1.44 illness (1.39-1.40) (1.43-1.44) Excess deaths from 1.45 1.51 respiratory illness (1.45-1.46) (1.51-1.52) R estimate, mean (95% CI) 4-d generation interval Mortality outcome Exp dist. Delta dist. Deaths from respiratory 1.54 1.62 illness (1.54-1.54) (1.62-1.63) Excess deaths from 1.62 1.73 respiratory illness (1.62-1.63) (1.72-1.74) * Estimates are based on daily data. A generation interval of 3 or 4 d is assumed, with an exponential (exp) or a fixed (delta) distribution (dist.). R, reproduction number. Table 4. Estimates of the reproduction number across influenza pandemic locations in the Americas, 1918-19 * R estimate Location, north to Time of 3-d serial 6-d serial south pandemic wave interval interval Source 45 US cities 1918 autumn 1.7-1.8 2.5-3.3 (2,22) ([dagger]) ([dagger]) Toluca 1918 spring 1.6-1.8 2.4-3.1 (3) 1918 autumn 2.0-2.5 3.2-6.1 (3) Mexico City 1918 spring 1.3-1.3 1.7-1.8 (3) 1918 autumn 1.3-1.3 1.6-1.7 (3) Boyaca, 1918 Oct-Nov 1.4-1.5 1.8-2.3 This study Colombia Lima, Peru 1918 Nov- 1.3-1.4 1.6-2.0 (4) 1919 Feb * Values are based on a range of estimates provided by considering different distributions of the generation interval (exponentially distributed latent and infectious periods or fixed generation interval). R, reproduction number. ([dagger]) R estimates are based on the mean of the initial growth rates across 45 US cities.
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