Incorporating time postinoculation into a dose–response model of Yersinia pestis in mice

Authors


Yin Huang, Department of Civil, Architectural and Environmental Engineering, Drexel University, Curtis Hall, Room 251, 3141 Chestnut Street, Philadelphia, PA 19104, USA. E-mail: yh89@drexel.edu

Abstract

Aims:  To develop a time-dependent dose–response model for describing the survival of animals exposed to Yersinia pestis.

Methods and Results:  Candidate time-dependent dose–response models were fitted to a survival data set for mice intraperitoneally exposed to graded doses of Y. pestis using the maximum likelihood estimation method. An exponential dose–response model with the model parameter modified by an inverse-power dependency of time postinoculation provided a statistically adequate fit to the experimental survival data. This modified model was verified by comparison with prior studies.

Conclusions:  The incorporated time dependency quantifies the expected temporal effect of in vivo bacteria growth in the dose–response relationship. The modified model describes the development of animal infectious response over time and represents observed responses accurately.

Significance and Impact of the Study:  This is the first study to incorporate time in a dose–response model for Y. pestis infection. The outcome may be used for the improved understanding of in vivo bacterial dynamics, improved postexposure decision making or as a component to better assist epidemiological investigations.

Introduction

Plague is caused by Yersinia pestis, a Gram-negative, facultative anaerobic, bipolar-staining, rod-shaped bacterium belonging to the family Enterobacteriaceae (Perry and Fetherston 1997). Plague may be manifested in three forms: bubonic, pneumonic and septicaemic (Lathem et al. 2005). An outbreak of plague in western China from September to October 2004 (Danzhou and Ding 2006) was the latest demonstration that plague continues to be a disease of concern.

While over 200 mammalian species have been reported to be naturally infected with Y. pestis, rodents are the most important hosts for plague (Perry and Fetherston 1997). Currently, most human plague cases in the world are classified as sylvatic plague, namely infection from rural wild animals such as mice, chipmunks, squirrels, gerbils, marmots, voles and rabbits (Christie 1982; Gage et al. 1992; Craven et al. 1993).

Transmission between rodents is achieved by their associated fleas from the infected blood of the host. The organism is not transovarially transmitted from flea-to-flea, and artificially infected larvae clear the organism within 24 h. Therefore, maintenance of plague in environment is dependent upon cyclic transmission between fleas and mammals (Bibikova 1977; Perry and Fetherston 1997).

Substantial early studies (Goldberg et al. 1954; Ehrenkranz and Meyer 1955; Holdenried and Quan 1956; Speck and Wolochow 1957; Lathem et al. 2005) have been conducted on the animal dose response for Y. pestis and the low LD50 reported indicates that Y. pestis is highly infectious. However, none of the prior studies reported the incubation time distributions for plague. Therefore it is desirable to use animal survival data from plague experiments for developing an understanding of the dose–response characteristic to Y. pestis infection over time. The results of this study are aimed at developing a time-dependent dose–response model for describing and predicting Y. pestis infection.

Method

Overview

This study consisted of the following steps:

  • 1 selection and characterization of survival data sets for analysis
  • 2 analysis of survival data via ‘classical’ dose–response modelling techniques
  • 3 development of empirical time-dependent dose–response models via analysis of survival data
  • 4 fitting of survival data with empirical dose–response models and selection of the best model
  • 5 verification of the best fit model via fitting of two additional dose–response data sets.

Source of data

The data used for development of a time-dependent dose–response model in the current study were drawn from a prior study (Rogers et al. 2007). The survival data presented in Table 1 were obtained from personal communication with J.V. Rogers (personal communication, Battelle Memorial Institute).

Table 1.   Response of Balb/c mice after interperitoneal exposure to graded doses of Yersinia pestis CO92 strain (Rogers et al. 2007)
Number of miceDose (CFU)Number of deaths at indicated time post inoculation (days)
01234567891011121314
  1. *All animals in dose group dead.

20  2000000000000000
20  8000121000100000
20 26000163201000000
10 74000450000000000
1025700028*         

In the study by Rogers et al. (2007), Y. pestis CO92 was cultured in 250 ml of heart infusion broth at 26°C on a rotary shaker at 250 rev min−1 prior to use. After 24 h of incubation, culture aliquots were diluted with sterile Dulbecco’s phosphate-buffered saline containing 0·01% gelatine to achieve target concentrations. Balb/c mice were injected intraperitoneally with the above sterile diluent (N = 10) and all target doses of Y. pestis (N = 10–20 per dose) and monitored for a period of 14 days to assess mortality.

Determination of the best model among classical dose–response models

Exponential, beta-Poisson and log-probit models have been used widely for risk assessment (Haas et al. 1999), and in this analysis they were evaluated for fit. The equations of exponential, beta-Poisson and log-probit models are shown as eqns (1)–(3) respectively.

image(1)
image(2)
image(3)

In eqns (1)–(3), d is dose, k, N50, α, q1 and q2 are parameters of the distributions, and ϕ denotes the cumulative normal distribution.

Maximum likelihood estimation (MLE) as described by Haas et al. (1999) was implemented into the R programming language (http://www.r-project.org, accessed on 8 August 2007) to fit these models to dose–response data. In the case of the exponential and beta-Poisson models the Broyden–Fletcher–Goldfarb–Shanno algorithm was used for optimization, and the Nelder–Mead algorithm was used for the log-probit model (Haas and Jacangelo 1993; Haas et al. 1999). By fitting the above-mentioned models with data in Table 1, their parameters and deviances were determined. To determine the goodness of the fits, the deviances were compared to the critical values of the chi-squared distribution at a 95% confidence level inline image, where df is the degree of freedom, m is the number of doses, n is the number of parameters. To determine the best model, the differences of deviances of candidate models were compared to the critical values of chi-squared distribution at a 95% confidence levelinline image, where Δdf is the difference of their degrees of freedom.

Identification of the time dependency of parameters

Since responses of mice to Y. pestis vary not only with the dose, but also with the time postinoculation (TPI), it is desirable to incorporate the factor of time into the classical model to describe the response pattern comprehensively.

For this reason, the parameter estimates in the best model were plotted against TPI via regression function implemented in the R programme to verify whether there is a discernable trend.

Fitting time-dependent dose–response data using MLE

Denoting the cumulative probability distribution for number of deaths occurring at dose di and at time tj after inoculation as F(di, tj), the predicted mortality of animals among surviving animals demonstrating a response during the time period tj-1 to tj is

image(4)

The probability of observing p positive responses among surviving animals during the time period j to j+1 is

image(5)

where pi,j is the number of positive responses observed during time period j to j+1, ni,j is number of surviving animals at the beginning of time period.

The constants in F(di, tj), were determined using MLE. The likelihood function for the set of observations made over j days for i dose groups is

image(6)

where mdoses is the total number of dose groups and mtimes is the number of time periods during which observations were made.

The corresponding deviance is

image(7)

This expression is nearly the same as that used in fitting classical dose–response data in which only the long-term endpoint is known (Haas et al. 1999). The differences between this expression and the expression normally used in dose–response modelling are that there is a double sum in the deviance expression, and that p is the number of positive responses in a time period rather than at the end of observations.

The minimized deviances of the modified and original models were determined using MLE. To test if a more complex model with more parameters provides a statistically better fit compared with the original one, the improvement to the deviance provided by the additional parameters was compared with the chi-squared distribution at 95% confidence level inline image (Haas et al. 1999).

Verification of the modified dose–response model

The modified model with time dependency was verified by comparison with observed dose–response data from two previous studies.

A response data set of Albino mice to the doses of Y. pestis was drawn from the early work of Holdenried and Quan (1956) and is shown in Table 2. In this work, the Alexander strain of Y. pestis was grown for 24 h at 28°C in brain–heart infusion broth and dilutions of the broth from 10−1 to 10−8 in 1% peptone water prepared. Each rodent was inoculated intracutaneously into a shaven area over the right thigh. A predicted response by the modified model was compared with the observed response.

Table 2.   Response of Albino mice exposed to the dose of Yersinia pestis Alexander strain via intracutaneous route (Holdenfried and Quan 1956)
TPI (days)Dose (CFU)Number of deathsNumber of survivors
171011
175412
1710142
17100151
171000170
1710 000161
17100 00060
171 000 00060

A survival response data set of guinea pigs exposed to the Y. pestis L.37 strain was drawn from the work of Druett et al. (1956) and is presented in Table 3. In this work, bacterial suspensions were prepared from growth on de-ionized casein partial hydrolysate medium incubated at 28°C. The suspension was then diluted in phosphate buffer (pH 7·6) to give the required number of organisms per millilitre. Guinea pigs weighing 350–450 g were exposed to 12 μm diameter particles carrying various amounts of Y. pestis organisms via the inhalation route. The percentages of deaths in Table 3 were converted into cumulative fraction mortality, with which the modified dose–response model was compared using the nonlinear least-squares (NLS) method.

Table 3.   Response of guinea pigs after exposure to aerosols of 12 μm particles containing organisms of Yersinia pestis L.37 strain (Druett et al. 1956)
Range of doses* (103 organisms)Percentage of deaths at indicated TPI (days)
1234567891011121314151617
  1. *Doses are based on data from the original work assuming a respiratory minute volume of 0·1 l min−1 (Kleinman and Radford 1964).

0–20001141261166000000000
20–50001354131048000000000
50–1000095818742200000000
100–200002843781·4434001·40000
200–500002757660001·50000003
500–100000384010444000000000

Results

Fits of the classical models to survival data

By applying the MLE method implemented in the R language, exponential, beta-Poisson and log-probit models were fitted to the data in Table 1, and the results are shown in Table 4. inline image was obtained for each TPI from the chi-squared table under the corresponding degree of freedom and confidence level. The deviances and differences of deviances were compared to the values of the chi-squared distribution at a 95% confidence level. Since minimized deviances are all less than inline image, the models provided an acceptable degree of fit. Since the differences of deviances between the one-parameter exponential model and the two-parameter beta-Poisson and log-probit models were less than inline image, the simpler exponential model is preferred.

Table 4.   Dose–response model parameter estimates for response noted at the end of each day from the experiment of interperitoneal exposure of mice to Yersinia pestis (Rogers et al. 2007)
TPI (days)Number of dosesModelParametersMinimized devianceinline imageAcceptable fit?ΔYinline image
  1. Exp denotes exponential, B-P denotes beta-Poisson, L-P denotes log-probit, and ΔY is the difference of deviances between one- and two-parameter models.

35Expk = 0·002247·0669·488Yes  
B-Pα = 0·153, N50 = 2395·2474·2137·8152·8533·843
L-Pq1 = 2·600, q2 = 799·6724·5197·8152·5473·843
45Expk = 0·02063·0689·488Yes  
B-Pα = 418435·9, N50 = 33·6033·0687·81503·843
L-Pq1 = 0·979, q2 = 28·7622·3227·8150·7463·843
55Expk = 0·02682·3019·488Yes  
B-Pα = 78867·4, N50 = 25·9022·3017·81503·843
L-Pq1 = 1·008, q2 = 22·4751·1077·8151·1943·843
65Expk = 0·03062·7079·488Yes  
B-Pα = 61225·3, N50 = 22·6452·7077·81503·843
L-Pq1 = 0·962 q2 = 19·8410·5577·8152·153·843
75Expk = 0·03062·7079·488Yes  
B-Pα = 61225·3, N50 = 22·6452·7077·81503·843
L-Pq1 = 0·962 q2 = 19·8410·5577·8152·153·843
85Expk = 0·03273·2409·488Yes  
B-Pα = 51016·4, N50 = 21·1713·2407·81503·843
L-Pq1 = 0·935, q2 = 18·6660·5627·8152·6783·843
95Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843
105Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843
115Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843
125Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843
135Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843
145Expk = 0·03453·1169·488Yes  
B-Pα = 78129·75, N50 = 20·1163·1167·81503·843
L-Pq1 = 0·989, q2 = 17·5900·8857·8152·2313·843

Incorporating time dependency into dose–response models

In the exponential model, the k parameter is the probability that a single micro-organism can survive, replicate and initiate infection. A single micro-organism, having survived, can replicate and colonize, and this process will increase the probability that a response (morbidity or mortality) occurs over time. Hence it is reasonable to expect that as TPI increases, the risk will increase. To quantify this in the exponential model, it is plausible to regard k as a time-dependent parameter.

Estimates for the exponential parameter k for individual days were plotted as a function of TPI and trends were assessed via nonlinear regression using r. Certain relationships between the parameter and inverse TPI (1/TPI) appeared to provide acceptable fits to the trend. Fits for two inverse models were plotted along with parameter estimates in Fig. 1. The two inverse models (solid line and dashed line) provided reasonable fits to the data for TPI >3 days but provided negative values of the parameter as TPI goes to zero. Noting that no deaths were observed in the experimental data before day 3, the following time-dependent dose–response models were proposed for evaluation:

image(8)
Figure 1.

 Trend line for exponential model parameter estimates as a function of TPI. • denotes parameter k; (----) represents the model inline image; (- - - -) represents the model inline imageinline image.

where, for the inverse model the expression for k is

image(9)

where k0 and k1 are parameters to be determined using MLE; for the inverse-power model, the expression for k is

image(10)

where k0, k1 and k2 are parameters to be determined using MLE. Noting that as TPI becomes very large, the modified model becomes the exponential model.

One additional time dependency of k was evaluated in this study. According to the gamma-distributed incubation time proposed by Teunis et al. (1999), an alternative expression for k is given by

image(11)

where k0 is a constant; inline image is the cumulative distribution function of gamma distribution; r is the shape parameter and β is the scale parameter.

The variation with time in the parameter k, which is equal to the probability that an ingested organism produces an infectious focus (response), does not imply that the ultimate ability of an individual organism to cause infection is changed. Rather, k(T) is the probability that an organism survives, multiplies and causes a response at or before time T.

Comparison of time-dependent dose–response models

The modified exponential models (eqns 8–11) were fitted to the survival data presented in Table 1 using MLE. The parameter estimates and the minimized deviances are listed in Table 5. The three-parameter exponential model with inverse-power TPI dependency proved to be the best model among the candidate models. It provided the lowest deviance, and gave a statistically significant improvement in fit over the two-parameter inverse model by reducing the deviance by more than inline image. It also provided a lower deviance compared with the sum of deviances of original exponential model on individual days. The exponential model with gamma-distributed TPI dependency showed a statistically acceptable fit but did not provide the lowest deviance. Bootstrap analysis (Haas et al. 1999) using R with 1000 iterations, as shown in Fig. 2, shows that the parameters of the exponential inverse-power model and their ratio were bounded tightly by the confidence intervals.

Table 5.   Optimal parameters and minimized deviances for time-dependent dose-response models fitted to survival data of mice exposed to Yersinia pestis (Rogers et al. 2007)
ModelData groupNumber. of parametersMinimized devianceinline imageAcceptable fit?
Exponential with inverse-power dependency Data pooled for 14 days (day 1 to day 14)3 (k0 = −0·500, k1 = 0·0355, k2 = 2·467)22·51575·624Yes
Exponential with inverse dependencyData pooled for 14 days (day 1 to day 14)2 (k0 = −0·145, k1 = 0·0506)27·47176·778Yes
Exponential with gamma-distributed dependencyData pooled for 14 days (day 1 to day 14)3 (k0 = 0·0368, r = 15·411, β = 3·408)31·92975·624Yes
Exponential without dependencyData for individual days (day 3 to day 14)1239·78565·171Yes
Figure 2.

 Bootstrap of the optimal parameters of exponential dose–response model with inverse-power TPI dependency fitted to survival data (Rogers et al. 2007).

The exponential inverse-power model was plotted to compare with the observed mortalities. The clear effects of the modification of the model on the different TPI groups and dose groups are shown in Figs 3 and 4 respectively. It can be seen that the modified exponential model is closely aligned with the data.

Figure 3.

 Exponential dose–response model with inverse-power TPI dependency (curves) compared to observed mortalities against doses (points) from the study of Rogers et al. (2007). (□, inline image) day 3, (bsl00084, inline image) day 4, (+, inline image) day 5, (×, inline image) day 6, (◊, inline image) day 7, (○, inline image) day 8, (*, inline image) day 9.

Figure 4.

 Exponential dose–response model with inverse-power TPI dependency (curves) compared to observed mortalities against TPI (points) from the study of Rogers et al. (2007). (○, inline image) 2 CFU, (bsl00084, inline image) 8 CFU, (+, inline image) 26 CFU, (×, inline image) 74 CFU, (◊, inline image) 257 CFU.

Comparison and verification between the modified exponential model and early studies

Figure 5 shows the comparison between the Y. pestis dose–response data drawn from the Holdenfreid and Quan (1956) study (Table 2) and the predicted curve. The curve was plotted according to the exponential inverse-power model with TPI equal to 17 and with the optimal parameter estimates in Table 5. As shown in Fig. 5, although with different strains of Y. pestis and mice, the modified model well predicted the observed experimental response.

Figure 5.

 Predicted dose–response using the modified exponential model compared to the observed response from the study of Holdenfried and Quan (1956). (Δ), observed response; (- - - -) predicted response.

As shown in Fig. 6, the exponential inverse-power model was fitted to the survival data of guinea pigs (Druett et al. 1956) using NLS. It can be seen that the modified model closely represents the survival reported in the independent study, showing adequate model flexibility.

Figure 6.

 Comparison between exponential dose–response model with inverse-power TPI dependency (curves) and the survival response data (points) from the study of Druett et al. (1956). (□, inline image) 0–20 (103 organisms), (bsl00084, - - - -) 20–50 (103 organisms), (+, .....) 50–100 (103 organisms), (×, inline image) 100–200 (103 organisms), (◊, inline image) 200–500 (103 organisms), (○, inline image) 500–1000 (103 organisms).

Discussion

It is well known that infection is a time-dependent process (Williams 1965), and phenomenological responses of animals to bacteria vary not only with the initial dose of micro-organisms, but also with the TPI, i.e. incubation time, with infectious agents. TPI is therefore one of the most important factors required for better describing or predicting the long-term effects of infectious diseases. For chemicals, the received dose is the total amount available to cause a response. However, micro-organisms have the ability to replicate, thus a different aspect needs to be considered in microbial risk assessment, not only the ability of the initial dose to survive but the extent to which it multiplies in the host species. This resulting amplified body burden may be the ultimate cause of the biological effect. To describe this issue comprehensively, it is desirable to incorporate the factor of time into the classical dose–response models. In this study, the incorporation of TPI yielded a modified exponential model capable of describing pooled time-dependent survival data and provided significant improvements to the fits.

An advantage of modifying the exponential model to include TPI effects is that the new model retains positive features of the exponential model including a mechanistic basis and linearity at low dose, which is similar to the beta-Poisson model. The log-probit model does not have a strong biological basis and does not exhibit linearity at low dose. Although the gamma-distributed dependency did not provide the best fit in this study, it still allows the possibility for future study that parameters of dose–response models could be modified by certain probability distribution functions of TPI with stronger theoretical basis over pure empirical models.

As mentioned previously, dose–response data taken from studies with different species of rodents (mice and guinea pigs) and inoculation routes (intraperitoneal, intracutaneous and inhalational) were used in this study in order to evaluate the robustness of the proposed time-dependent dose–response model. Despite their differences, the data sets were well described by the modified model with the same functional form. This result indicates that the model is of an appropriate form and flexibility to describe Y. pestis infection occurring in rodent species for which the survival dose–response data are currently available. In other words, host and inoculation route differences are manifest only on the parameter values and not on the functional form. Further study on the impact of hosts from different orders of mammals (e.g. nonhuman primates) and inoculation routes on the model robustness is currently in progress.

The doses shown in Table 3 were estimated from the data of original work of Druett et al. (1956). The range of dosage presented in the original work was defined as Nt × 10−4, where N is the number of bacteria per litre air and t is exposure time in minutes. Hence, in this study the dosage was transformed into the number of organisms inhaled by taking the product of the respiratory minute volume (litre air per minute) of the host and the factor 104. For guinea pigs weighing 350–450 g, the respiratory minute volume is approximately 0·1 l min−1 (Kleinman and Radford 1964). However, it should be noted that the dose levels listed in Table 3 are still not reflective of the actual number of viable Y. pestis cells delivered into the respiratory system of the host. To calculate the number of micro-organisms inhaled with precision, one would need to know the death rate of organisms in the air, as Y. pestis is a very labile organism when airborne (Druett et al. 1956). This labile nature may explain the discrepancy in the LD50 dose via the respiratory route as compared with the subcutaneous one (Druett et al. 1956).

Noticeably in both studies of Druett et al. (1956) and Rogers et al. (2007), the deaths of mice as a response to exposure to Y. pestis took place from the third day and reached the highest rate on the fourth day. The critical TPI for the highest mortality rate to occur can be explained by comparison with previous kinetic studies of in vivo microbial growth (Lathem et al. 2005; Sebbane et al. 2005). In the study by Lathem et al. (2005), the pathogen load increased logarithmically in the spleens and lungs of mice, and deaths occurred by 72 h after intranasal inoculation of 104 CFU Y. pestis strain CO92. Sebbane et al. (2005) showed that rats succumbed due to heavy proliferation of bacteria by 72 h after intradermal inoculation of 600 CFU Y. pestis strain 195/P. The substantial increase in deaths between the third and the fourth day is consistent with rapid bacterial colonization and high pathogen load in animal organs after 72 h postinoculation. In view of the 2–6 days incubation period of human bubonic plague (Benenson 1970), a possibly similar pattern of bacteria proliferation in human and mice host may exist but remains to be verified.

As described by Nishiura (2007) knowledge of incubation period distributions may be used in numerous clinical, public health and ecological studies. These potential uses of improved time-dependent dose–response models which merit the understanding of incubation period are:

  • 1 estimation of time of exposure for a point-source outbreak
  • 2 determining whether case onset is over in the event of an outbreak
  • 3 early projection of disease prognosis when incubation period is associated with clinical severity
  • 4 development of mechanistic models for infection and illness

It is feasible that by using a similar approach to examine and include the potential time dependencies into dose–response models for other pathogens and exposure routes, the temporal distributions of infections and mortalities may be described more comprehensively. Furthermore, the approach of this study demonstrates that response models may be quantitatively improved by incorporating additional physical and biological factors, e.g. the age of host and the administrated dose of antibiotics.

Acknowledgements

The authors thank Joanna M. Pope (PhD candidate at Drexel University) for advice, and thank J.V. Rogers for providing unpublished raw data. This research was funded through the Centre for Advancing Microbial Risk Assessment, supported by the US Environmental Protection Agency and US Department of Homeland Security, under the US EPA Science to Achieve Results (STAR) grant program (grant number: R83236201).

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