Estimates of outbreak risk from new introductions of Ebola with immediate and delayed transmission control.
Although none of these introductions led to a long chain of transmissions, even a small outbreak in a new country can cause societal disruption and disproportionate costs (17). Furthermore, how likely it is that an introduced case will lead to a substantial number of transmissions is unclear, even in settings with a quick and vigorous public health response to new outbreaks. Gomes et al. (4) performed simulations of Ebola outbreaks in each of 220 countries by first estimating the risk of Ebola being exported from Guinea, Liberia, or Sierra Leone by international travelers and then simulating a stochastic Ebola transmission model conditioned on an importation. The model incorporated Ebola transmission from infected persons in the community and hospital settings and from recently deceased Ebola patients. Assumptions used in the model were that only community transmissions are relevant outside of Africa and that transmissions occur at rates corresponding to containment measures already in place. Gomes et al. provided no explicitly numerical probabilities of large outbreaks per importation, but their simulations apparently produced <100 cases in each country.
In another study, Rainisch et al. (18) calculated the estimated number of beds required to treat Ebola patients in the United States by using estimates of importation frequency and subsequent transmission. These researchers reported a high estimate of 7 beds (95% CI 2-13) required at any 1 time; they also provided no numerical probabilities for their estimates.
In our study, we use a branching process model to estimate the probability distribution of outbreak sizes resulting from the introduction of an Ebola case to a new country where the reproductive number R (i.e., expected number of transmissions per case) would likely be quickly, if not immediately, reduced to <1. In this scenario, theory from subcritical branching processes (19), also known as mortal branching processes (20), guarantees that an outbreak will eventually die out, although perhaps not before a substantial number of transmissions occur. In the modeling literature, outbreaks that die out on their own have been called minor outbreaks (21) or stuttering chains (22). Such branching process models have been used to estimate transmission parameters in the context of emerging (22,23) or reemerging (19-21,24) infectious diseases. However, unlike other studies, we used the outbreak final size distribution equations derived from branching process theory to calculate the risk for a large Ebola outbreak under the assumptions of immediate and delayed transmission control after an importation.
Materials and Methods
We first gathered transmission data for all Ebola patients who were documented in the ongoing West Africa outbreak and who spent all or part of their infectious periods in a country other than Guinea, Sierra Leone, or Liberia. We next fit the negative binomial distribution to the transmission data and to various data subsets according to patients' circumstances. We also applied the theory of branching processes with a negative binomial offspring distribution to estimate the probability that new introductions would lead to outbreaks exceeding various sizes. We then organized these estimates under 2 scenarios of transmission control: immediate and delayed. For each scenario, we tested the effects of different levels of variability in transmission.
In the data-gathering step, we compiled information for 56 documented Ebola patients (Table 1) who spent all or part of their infectious period in 1 of 12 countries other than Guinea, Sierra Leone, or Liberia. We broke these data into 3 subgroups: patients who traveled to 1 of the 12 countries during their incubation or symptomatic period, patients deliberately evacuated from West Africa for treatment, and patients who acquired infection in the new country after an introduction of the virus.
We fit the transmission data from patients within subgroups to the negative binomial distribution with mean R and dispersion parameter k, which characterizes individual variation in transmission, including the likelihood of superspreading events (i.e., when infected persons disproportionately transmit the virus to others) (25). High values of k produce low variability and a low probability of superspreading; k approaching infinity leads to a Poisson distribution, which arises when all infected persons have an equal expected number of contacts and an equal probability of transmission per contact. The value k = 1 corresponds to a geometric distribution, which arises when the duration of the infectious period varies among infected persons according to an exponential distribution, as is generally assumed by differential equation models; otherwise, the infected persons are homogeneous. Values of k <1 produce more highly dispersed models, which occur when infected persons vary substantially in numbers of susceptible contacts or in probabilities of transmission per contact (25). Occurrence of high variability leads to a higher probability of superspreading.
We estimated the parameters R and k for each data subset by using the method of moments, which calculates the parameter values that produce the exact mean and variance exhibited by the data (i.e., a single estimate for R and k). We calculated associated confidence intervals by using a bias-corrected percentile method (26) on random samples of the data. We also used a Kolmogorov-Smirnov test (27) to assess goodness of fit (online Technical Appendix, http://wwwnc.cdc.gov/EID/article/21/8/15-0170Techapp1.pdf).
We then applied theory from branching process models, which use a discrete probability distribution, or offspring distribution, to specify the number of transmissions resulting from each infected person in a chain of transmissions. We used the negative binomial distributions fitted to the Ebola transmission data for the offspring distribution. Because our R estimates differed depending on the data subgroups representing each infected person's circumstances, we examined models representing an immediate control scenario and a delayed control scenario, each with 2 levels of control, for a total of 4 combinations of parameters.
In the immediate control scenario, the initial infected person or persons and any subsequent infected persons transmit infection according to the same distribution with R<1. In the delayed control scenario, the initially introduced infected person or persons have a higher expected number of transmissions ([R.sub.0], the initial or basic reproductive number) than the number expected to be transmitted from subsequent cases ([R.sub.c], the postcontrol reproductive number). The delayed control scenario can occur when an infected traveler arrives in a new country during the incubation or symptomatic period and has contact with others before the person has been identified as infected or when the person is treated in a facility that is not fully prepared or experienced in handling an Ebola patient, but any subsequent cases are identified quickly and handled more effectively by a well prepared facility. For controlled patients in either scenario, we examined 2 different levels of control; these levels are represented by 2 values of the postcontrol reproductive number: 1 derived from the average number of transmissions from evacuated infected persons and 1 from the average number of transmissions from persons who acquired infection locally. Because the k values calculated from the fitting of transmission data ranged widely, we applied a series of 3 test values (k = 0.1, 1, and 10) to each scenario to determine the effect of variability on the outcomes.
For each scenario and each set of parameter assumptions, the probability distribution of final outbreak sizes according to branching process theory can be calculated (online Technical Appendix) as examples of Lagrangian distributions (28,29). For each parameter combination, we used these equations to calculate the probability of exceeding given outbreak sizes, up to the size expected to be exceeded with a probability of [approximately equal to]0.01%. To compare different scenarios, we calculated the probability of exceeding 10 and 100 total transmissions and worst-case outbreak sizes (i.e., the number of transmissions expected to be exceeded after 1% and 0.01% of introductions of Ebola). Although we show only results calculated with the assumption of 1 initial patient, the equations we provide (online Technical Appendix) generalize to any number of initial patients and can be used in situations for which multiple introductions might be of interest.
Certain subgroups of patients within the dataset produced substantially different R estimates (Table 2). For patients who traveled to 1 of the 12 countries during their incubation or symptomatic period, we calculated R = 2.9 transmissions per patient; for patients deliberately evacuated from West Africa for treatment, R = 0.05; for patients who acquired infection in the new country after an introduction, R = 0.3. Estimates of k produced wide CIs within subgroups, from values <1, which are consistent with a highly dispersed distribution, to large values, which are consistent with a Poisson distribution.
Assuming [R.sub.0] = 3, estimated on the basis of traveler-imported cases, and [R.sub.c] = 0.3, estimated on the basis of locally acquired cases, the chance of an outbreak with [greater than or equal to]10 transmissions after a single introduction ranges from [approximately equal to]7%-13% across the 3 assumed values for k: 0.1, 1, and 10 (Figure 1, panel A). The chance of an outbreak with [greater than or equal to] 100 transmissions is negligible (<0.01%) for k = 10 and k = 1 but rises to [approximately equal to]0.4% under a high variability assumption of k = 0.1 because of increased likelihood of superspreading. We considered the effect of 2 ways to reduce the risk from those results: decreasing [R.sub.c] to approach the level of control achieved among evacuated patients (30) and eliminating the initial high-average transmission step to reflect preidentification of the initial infected traveler.
When [R.sub.0] = 3 but [R.sub.c] is decreased to 0.1 (Figure 1, panel B), the chance of >10 transmissions is 1%-10%. The chance of [greater than or equal to]100 transmissions is <0.01% for k = 10 and k = 1 and 0.2% with high variability. Assuming that the initial patient is identified and that transmission is controlled (R = 0.3) (Figure 1, panel C) causes a much more substantial decrease in outbreak risk, to a range of 0.04%-1% for [greater than or equal to]10 transmissions and <0.01% for [greater than or equal to]100 transmissions, even with high variability. Assuming R = 0.1 for all patients causes [greater than or equal to]10 transmissions to be very unlikely, with a 0.01% chance even with high variability (Figure 1, panel D).
In addition, we compared the 4 scenarios and considered worst-case outbreaks at 2 probability levels: the outbreak level estimated by the model to be exceeded in 1% of introductions (Figure 2, panel A) and the outbreak level estimated by the model to be exceeded in 1 in 10,000 introductions (Figure 2, panel B). The effect of identifying the initial patient is stronger than the effect of reducing [R.sub.c], but the combination produces a synergistic effect. For example, at moderate variability (k = 1), the 0.01% worst-case outbreak size when [R.sub.0] = 3 and [R.sub.c] = 0.3 (49 total transmissions) is reduced to 73% of that value (36 total transmissions) when [R.sub.c] is reduced to 0.1. The worst-case outbreak size is reduced to 31% (15 total transmissions) when the initial patient is identified. Reducing [R.sub.c] (i.e., postcontrol average number of transmissions per patient) and identifying the initial patient together decrease transmission size to 10% of the worst-case value (5 total transmissions), which is greater than the expected reduction (to 22%) if each intervention was conducted independently. The worst-case risk reduction is greatest under the assumption of high transmission variability (k = 0.1); the 0.01% worst-case outbreak size is reduced from 239 total transmissions to 4% or 10 total transmissions when both intervention assumptions are applied.
We also explored the sensitivity of exceedance probabilities to additional values of R and k (online Technical Appendix Figure) and showed nuances of how higher variability can simultaneously increase the probability of the best-case scenario (no transmissions) and of worst-case scenarios (e.g., superspreading, which can lead to large outbreaks).
The outbreak size distributions produced by our models are comparable to those of Gomes et al. (4), although their results also encompassed frequencies of case exportations from Guinea, Sierra Leone, or Liberia into each particular country, which our analysis did not include. None of their simulations appears to have produced >100 cases in any particular country, indicating that our scenarios result in more pessimistic outcomes. For example, our delayed-control, high-variability (k = 0.1) scenario produced a 0.4% probability of >100 transmissions after a single introduction. The assumed transmission probabilities of Gomes et al. appear to be more comparable to our immediate-control and lower-variability scenarios.
Our estimates also assign greater potential probabilities of large outbreaks than those provided by Rainisch et al. (18), whose highest estimate of the number of beds required at a given time to treat Ebola patients in the United States was 7 (95% CI 2-13). The difference between this result and ours is farther widened because their result includes the possibility of multiple simultaneous introductions caused by a cluster of infected travelers, whereas our results were based on a single introduction. Their worst-case estimate is lower than ours because Rainisch et al. assumed a maximum of 2 additional cases caused by secondary transmission per imported case, whereas our fitted distributions of possible transmissions reach >2, sometimes with substantial probability. For example, in our scenario of a single unidentified traveler's Ebola introduction with [R.sub.0] = 3 and subsequent cases transmitting with [R.sub.c] = 0.3 and with moderate transmission variability (k = 1), our model estimates a 50% chance of >2 transmissions occurring after a single introduction. However, under the assumption of immediate transmission control (R = 0.1), our model estimates [less than or equal to]1% chance of >2 transmissions.
The contrasting relationships between the parameter k and different measures of outbreak risk reflect the unpredictable outcome of high variability in transmission: a low frequency of outbreaks after a new introduction but a relatively high probability of an explosive outbreak when an outbreak occurs. This situation was seen in countries experiencing introduced cases of severe acute respiratory syndrome, for which estimated values of k were [approximately equal to]0.1 (25). A recent study (31) produced a similar estimate (k = 0.18; 95% CI 0.10-0.26) when the negative binomial distribution was fitted to data from large Ebola transmission chains in Guinea (32); this result suggests that the high variability assumption may be appropriate, but whether or not the assumption of high variability is an appropriate characterization for potential Ebola outbreaks in new countries is unclear. Attempting to estimate k by using transmission data (Table 1) produced wide ranges of uncertainty. However, the Ebola case that resulted in 13 transmissions in Nigeria suggests that assuming a low value of k, at least for the delayed control scenario, is justified. In Nigeria, the average number of transmissions from those 13 and all subsequent cases was <0.4. This low average number of transmissions was assisted by health authorities' rapid implementation of control measures (5). Little evidence exists for high transmission variability from these or other locally acquired or medically evacuated Ebola cases.
Our framework quantitatively characterizes worst-case Ebola outbreaks resulting from an introduced Ebola case to a region with relatively effective control measures. Our results can be used by public health officials engaging in risk-benefit analyses of potential decisions affecting Ebola case introductions, such as decisions to evacuate infected or potentially infected persons from West Africa, policies on travel surveillance measures, and strategies for handling identified importations. Initial public health assessments at the local level include the risk of importing a case to that geographic area (4,18,33,34), the cost versus benefit of identifying potential cases through traveler screening (i.e., in major international ports of arrival), or surveillance in health care facilities (that serve populations at risk from travel or exposure). Either way, the tried and tested methods of early detection and isolation appear to be of primary importance in controlling ongoing Ebola outbreaks in West Africa (35) or potential new outbreaks caused by imported cases elsewhere.
Our framework also provides a simple method to quantify the individual and synergistic effects of different control strategies. Our results stress the paramount importance of surveillance measures to identify international travelers who may have been recently exposed to Ebola virus because a higher reproductive number from initially introduced cases can drastically increase the risk of a large outbreak, even if effective control measures are immediately put in place to reduce transmission from subsequent cases. Surveillance, combined with measures to reduce transmission from local cases to the low average achieved among evacuated cases (30), can reduce the probability of all but a handful of transmissions to negligible levels.
Author affiliations: University of Utah, Salt Lake City, Utah, USA (D.J.A. Toth, A.V. Gundlapalli, K. Khader, W.B.P. Pettey, M.A. Rubin, F.R. Adler, M.H. Samore); US Department of Veterans Affairs Salt Lake City Health Care System, Salt Lake City (D.J.A. Toth, A.V. Gundlapalli, K. Khader, W.B.P. Pettey, M.A. Rubin, M.H. Samore).
Dr. Toth is an assistant professor in the Division of Epidemiology, Department of Internal Medicine, University of Utah School of Medicine, Salt Lake City, UT, USA. His research interest is applied mathematics, specifically mathematical modeling of infection and transmission of pathogens to support risk assessment and intervention planning for public health.
(1.) Baize S, Pannetier D, Oestereich L, Rieger T, Koivogui L, Magassouba N, et al. Emergence of Zaire Ebola virus disease in Guinea. N Engl J Med. 2014;371:1418-25. http://dx.doi.org/ 10.1056/NEJMoa1404505
(2.) Centers for Disease Control and Prevention. 2014 Ebola outbreak in West Africa--outbreak distribution map. 2015 Apr 17 [cited 2015 Apr 24]. http://www.cdc.gov/vhf/ebola/outbreaks/ 2014-west-africa/distribution-map.html
(3.) Centers for Disease Control and Prevention. Outbreaks chronology: Ebola virus disease. 2015 Apr 24 [cited 2015 Apr 24]. http://www.cdc.gov/vhf/ebola/outbreaks/history/chronology.html
(4.) Gomes MFC, Postore y Piontti A, Rossi L, Chao D, Longini I, Halloran ME, et al. Assessing the international spreading risk associated with the 2014 West African Ebola outbreak. PLoS Curr Outbreaks. 2014 Sep 2. Edition 1. http://dx.doi.org/10.1371/ currents.outbreaks.cd818f63d40e24aef769dda7df9e0da5
(5.) Fasina FO, Shittu A, Lazarus D, Tomori O, Simonsen L, Viboud C, et al. Transmission dynamics and control of Ebola virus disease outbreak in Nigeria, July to September 2014. Euro Surveill. 2014;19:20920.
(6.) Shuaib F, Gunnala R, Musa EO, Mahoney FJ, Oguntimehin O, Nguku PM, et al. Ebola virus disease outbreak--Nigeria, July-September 2014. MMWR Morb Mortal Wkly Rep. 2014;63: 867-72.
(7.) McCarty CL, Basler C, Karwowski M, Erme M, Nixon G, Kippes C, et al. Response to importation of a case of Ebola virus disease--Ohio, October 2014. MMWR Morb Mortal Wkly Rep. 2014;63:1089-91.
(8.) Chevalier MS, Chung W, Smith J, Weil LM, Hughes SM, Joyner SN, et al. Ebola virus disease cluster in the United States--Dallas County, Texas, 2014. MMWR Morb Mortal Wkly Rep. 2014;63:1087-8.
(9.) World Health Organization. Mali: details of the additional cases of Ebola virus disease. 2014 Nov 20 [cited 2015 Apr 24]. http://www.who.int/mediacentre/news/ebola/20-november2014-mali/en/
(10.) World Health Organization. Mali confirms 2 new cases of Ebola virus disease. 2014 Nov 25 [cited 2015 Apr 24]. http://www.who.int/ mediacentre/news/ebola/25-november-2014-mali/en/
(11.) World Health Organization. Mali case, Ebola imported from Guinea. 2014 Nov 10 [cited 2015 Apr 24]. http://www.who.int/ mediacentre/news/ebola/10-november-2014-mali/en/
(12.) Mirkovic K, Thwing J, Diack PA. Importation and containment of Ebola virus disease--Senegal, August-September 2014. MMWR Morb Mortal Wkly Rep. 2014;63:873-4.
(13.) Centers for Disease Control and Prevention. Cases of Ebola diagnosed in the United States. 2014 Dec 16 [cited 2015 Apr 24]. http://www.cdc.gov/vhf/ebola/outbreaks/2014-west-africa/ united-states-imported-case.html
(14.) Jenkins L. Nurse who contracted Ebola released from hospital. 2015 Jan 24 [cited 2015 Apr 24]. http://www.theguardian.com/ world/2015/jan/24/ebola-pauline-cafferkey-recovery-discharge
(15.) Public Health England. Ebola virus disease epidemiological update: no. 32. 2015 Apr 24 [cited 2015 Apr 24]. https://www.gov.uk/ government/uploads/system/uploads/attachment_data/file/423997/ EVD_Epidemiological_Update_24_April.pdf.
(16.) Gulland A. Spanish authorities investigate how nurse contracted Ebola. BMJ. 2014;349:g6120. http://dx.doi.org/10.1136/bmj.g6120
(17.) Szabo L. Costs of responding to Ebola adding up. 2014 Nov 25 [cited 2015 Apr 24]. http://www.usatoday.com/story/news/ nation/2014/11/25/ebola-costs-add-up/19346913/
(18.) Rainisch G, Asher J, George D, Clay M, Smith TL, Cosmos K, et al. Estimating Ebola treatment needs, United States [letter]. Emerg Infect Dis. 2015 Jul [cited 2015 Apr 27]. http://dx.doi.org/ 10.3201/eid2107.150286
(19.) Farrington CP, Grant AD. The distribution of time to extinction in subcritical branching processes: applications to outbreaks of infectious disease. J Appl Probab. 1999;36:771-9. http://dx.doi.org/ 10.1239/jap/1032374633
(20.) Becker N. On parametric estimation for mortal branching processes. Biometrika. 1974;61:393-9. http://dx.doi.org/10.1093/ biomet/61.2.393
(21.) Nishiura H, Yan P, Sleeman CK, Mode CJ. Estimating the transmission potential of supercritical processes based on the final size distribution of minor outbreaks. J Theor Biol. 2012; 294:48-55. http://dx.doi.org/10.1016/j.jtbi.2011.10.039
(22.) Blumberg S, Lloyd-Smith JO. Inference of R0 and transmission heterogeneity from the size distribution of stuttering chains. PLOS Comput Biol. 2013;9:e1002993. http://dx.doi.org/10.1371/journal. pcbi.1002993
(23.) Ferguson NM, Fraser C, Donnelly CA, Ghani AC, Anderson RM. Public health risk from the avian H5N1 influenza epidemic. Science. 2004;304:968-9. http://dx.doi.org/10.1126/ science.1096898
(24.) Jansen VAA, Stollenwerk N, Jensen HJ, Ramsay ME, Edmunds WJ, Rhodes CJ. Measles outbreaks in a population with declining vaccine uptake. Science. 2003;301:804. http://dx.doi.org/10.1126/ science.1086726
(25.) Lloyd-Smith JO, Schreiber SJ, Kopp PE, Getz WM. Superspreading and the effect of individual variation on disease emergence. Nature. 2005;438:355-9.
(26.) DiCiccio T, Efron B. Bootstrap confidence intervals. Stat Sci. 1996; 11:189-228. http://dx/doi.org/10.1214/ss/1032280214.
(27.) Arnold TB, Emerson JW. Nonparametric goodness-of-fit tests for discrete null distributions. R J. 2011;3/2:34-9.
(28.) Consul PC, Shenton LR. Use of Lagrange expansion for generating discrete generalized probability distributions. SIAM J Appl Math. 1972;23:239-48. http://dx.doi.org/10.1137/0123026
(29.) Consul PC, Famoye F. Lagrangian probability distributions. Boston: Birkhauser; 2006.
(30.) Centers for Disease Control and Prevention. Interim guidance for U.S. hospital preparedness for patients under investigation (PUIs) or with confirmed Ebola virus disease (EVD): a framework for a tiered approach. 2015 Feb 20 [cited 2015 Apr 24]. http://www.cdc.gov/vhf/ebola/hcp/us-hospital-preparedness.html
(31.) Althaus CL. Ebola Superspreading: the real lessons from HIV scale-up. Lancet Infect Dis. 2015;15:507-8. http://dx.doi.org/ 10.1016/S1473-3099(15)70135-0
(32.) Faye O, Boelle P, Heleze E, Faye O, Loucoubar C, Magassouba N, et al. Chains of transmission and control of Ebola virus disease in Conakry, Guinea, in 2014: an observational study. Lancet Infect Dis. 2015;15:320-6. http://dx.doi.org/10.1016/ S1473-3099(14)71075-8
(33.) Bogoch II, Creatore MI, Cetron MS, Brownstein JS, Pesik N, Miniota J, et al. Assessment of the potential for international dissemination of Ebola virus via commercial air travel during the 2014 west African outbreak. Lancet. 2015;385:29-35. http://dx.doi.org/10.1016/S0140-6736(14)61828-6
(34.) Rainisch G, Shankar M, Wellman M, Merlin T, Meltzer MI. Regional spread of Ebola virus, West Africa, 2014. Emerg Infect Dis. 2015;21:444-7. http://dx.doi.org/10.3201/eid2103.141845
(35.) Chowell D, Castillo-Chavez C, Krishna S, Qiu X, Anderson KS. Modelling the effect of early detection of Ebola. Lancet Infect Dis. 2015;15:148-9. http://dx.doi.org/10.1016/S1473-3099(14)71084-9
Address for correspondence: Damon J.A. Toth, Division of Epidemiology, Department of Internal Medicine, University of Utah School of Medicine, 295 Chipeta Way, Salt Lake City, UT 84132, USA; email: Damon.Toth@hsc.utah.edu
Table 1. Characteristics of Ebola case-patients reported outside Guinea, Sierra Leone, and Liberia * Case- Year and Country patients month 1 2014 Jul Nigeria 2-4 2014 Jul-Aug Nigeria 5-19 2014 Jul-Aug Nigeria 20 2014 Aug Nigeria 21-23 2014 Aug Spain, United Kingdom, Germany 24 2014 Aug Senegal 25-27 2014 Aug-Sep United States 28 2014 Sep France 29 2014 Sep United States 30 2014 Sep Spain 31-32 2014 Oct United States 33 2014 Oct Spain 34-35 2014 Oct Germany 36 2014 Oct Norway 37 2014 Oct United States 38 2014 Oct Mali 39-40 2014 Oct-Nov United States 41 2014 Nov France 42 2014 Nov Mali 43-44 2014 Nov Mali 45-49 2014 Nov Mali 50-52 2014 Nov United States, Switzerland, Italy 53 2014 Dec The Netherlands 54 2014 Dec United Kingdom 55-56 2015 Mar United Kingdom, United States Case- Circumstance No. patients of infection transmissions 1 Imported by traveler 13 2-4 Locally acquired 1 5-19 Locally acquired 0 20 Locally acquired 3 21-23 Evacuated 0 24 Imported by traveler 0 25-27 Evacuated 0 28 Evacuated 0 29 Imported by traveler 2 30 Evacuated 1 31-32 Locally acquired 0 33 Locally acquired 0 34-35 Evacuated 0 36 Evacuated 0 37 Imported by traveler 0 38 Imported by traveler 0 39-40 Evacuated 0 41 Evacuated 0 42 Imported by traveler 5 43-44 Locally acquired 1 45-49 Locally acquired 0 50-52 Evacuated 0 53 Evacuated 0 54 Imported by traveler 0 55-56 Evacuated 0 * These data are published and publicly available as of April 24, 2015. Month/year is when patients were transferred or diagnosed. References by country: Nigeria (5,6); Spain (15,16); United Kingdom (14,15); Senegal (12); United States (7,8,13,15); Mali (9-11); other countries (15). Table 2. Summary of Ebola data and parameter estimates * Patient group No. Transmissions All 56 29 Traveler 7 19 Evacuated patient 20 1 Patient with locally 29 9 acquired Ebola Patient group R estimate k estimate (90% CI) (90% CI) All 0.5 (0.2-1.0) 0.09 (0.03-0.2) Traveler 2.9 (0.6-6.1) 0.4 (0.2-1.3) Evacuated patient 0.05 (0-0.1) [infinity] Patient with locally 0.3 (0.1-0.5) 0.5 acquired Ebola (0.2-[infinity]) * Cases were included if the patient spent any of the infectious period in a country other than Guinea, Liberia, or Sierra Leone. The 56 patients are split into 3 mutually exclusive subgroups, depending on the patients' circumstances. Parameters R and k of the negative binomial distribution are the reproductive number and dispersion parameter, respectively. Goodness of fit was not rejected by a Kolmogorov-Smirnov test (p>0.6 in all cases).
|Printer friendly Cite/link Email Feedback|
|Author:||Toth, Damon J.A.; Gundlapalli, Adi V.; Khader, Karim; Pettey, Warren B.P.; Rubin, Michael A.; Adler,|
|Publication:||Emerging Infectious Diseases|
|Date:||Aug 1, 2015|
|Previous Article:||Prevalence of hepatitis E virus infection in pigs at the time of slaughter, United Kingdom, 2013.|
|Next Article:||Genomic assays for identification of chikungunya virus in blood donors, Puerto Rico, 2014.|